<?xml version="1.0" encoding="UTF-8"?><!DOCTYPE article PUBLIC "-//NLM//DTD Journal Publishing DTD v2.0 20040830//EN" "journalpublishing.dtd"><article xmlns:mml="http://www.w3.org/1998/Math/MathML" xmlns:xlink="http://www.w3.org/1999/xlink" dtd-version="2.0" xml:lang="en" article-type="review-article"><front><journal-meta><journal-id journal-id-type="nlm-ta">J Med Internet Res</journal-id><journal-id journal-id-type="publisher-id">jmir</journal-id><journal-id journal-id-type="index">1</journal-id><journal-title>Journal of Medical Internet Research</journal-title><abbrev-journal-title>J Med Internet Res</abbrev-journal-title><issn pub-type="epub">1438-8871</issn><publisher><publisher-name>JMIR Publications</publisher-name><publisher-loc>Toronto, Canada</publisher-loc></publisher></journal-meta><article-meta><article-id pub-id-type="publisher-id">v28i1e93496</article-id><article-id pub-id-type="doi">10.2196/93496</article-id><article-categories><subj-group subj-group-type="heading"><subject>Review</subject></subj-group></article-categories><title-group><article-title>Effectiveness of Wearable Digital Therapeutics in Improving Sleep Outcomes Among Individuals With Insomnia: Systematic Review and Meta-Analysis of Randomized Controlled Trials</article-title></title-group><contrib-group><contrib contrib-type="author"><name name-style="western"><surname>Zhu</surname><given-names>Wenhui</given-names></name><degrees>MMed</degrees><xref ref-type="aff" rid="aff1">1</xref></contrib><contrib contrib-type="author"><name name-style="western"><surname>Chen</surname><given-names>Mingming</given-names></name><degrees>MMed</degrees><xref ref-type="aff" rid="aff1">1</xref></contrib><contrib contrib-type="author"><name name-style="western"><surname>Guo</surname><given-names>Yixuan</given-names></name><degrees>MMed</degrees><xref ref-type="aff" rid="aff1">1</xref></contrib><contrib contrib-type="author" equal-contrib="yes"><name name-style="western"><surname>Zhang</surname><given-names>Bin</given-names></name><degrees>MD, PhD</degrees><xref ref-type="aff" rid="aff2">2</xref><xref ref-type="fn" rid="equal-contrib1">*</xref></contrib><contrib contrib-type="author" corresp="yes" equal-contrib="yes"><name name-style="western"><surname>Luo</surname><given-names>Chunliu</given-names></name><degrees>MMed</degrees><xref ref-type="aff" rid="aff2">2</xref><xref ref-type="fn" rid="equal-contrib1">*</xref></contrib></contrib-group><aff id="aff1"><institution>School of Nursing, Jinan University</institution><addr-line>Guangzhou</addr-line><addr-line>Guangdong</addr-line><country>China</country></aff><aff id="aff2"><institution>First Affiliated Hospital of Jinan University</institution><addr-line>613 Huangpu Avenue West</addr-line><addr-line>Guangzhou</addr-line><addr-line>Guangdong</addr-line><country>China</country></aff><contrib-group><contrib contrib-type="editor"><name name-style="western"><surname>Brini</surname><given-names>Stefano</given-names></name></contrib></contrib-group><contrib-group><contrib contrib-type="reviewer"><name name-style="western"><surname>Almashmoum</surname><given-names>Maryam</given-names></name></contrib><contrib contrib-type="reviewer"><name name-style="western"><surname>Xu</surname><given-names>Tong Bill</given-names></name></contrib></contrib-group><author-notes><corresp>Correspondence to Chunliu Luo, MMed, First Affiliated Hospital of Jinan University, 613 Huangpu Avenue West, Guangzhou, Guangdong, 510630, China, 86 18926202718; <email>jnuchll@163.com</email></corresp><fn fn-type="equal" id="equal-contrib1"><label>*</label><p>these authors contributed equally</p></fn></author-notes><pub-date pub-type="collection"><year>2026</year></pub-date><pub-date pub-type="epub"><day>11</day><month>9</month><year>2026</year></pub-date><volume>28</volume><elocation-id>e93496</elocation-id><history><date date-type="received"><day>15</day><month>02</month><year>2026</year></date><date date-type="rev-recd"><day>23</day><month>07</month><year>2026</year></date><date date-type="accepted"><day>25</day><month>07</month><year>2026</year></date></history><copyright-statement>&#x00A9; Wenhui Zhu, Mingming Chen, Yixuan Guo, Bin Zhang, Chunliu Luo. Originally published in the Journal of Medical Internet Research (<ext-link ext-link-type="uri" xlink:href="https://www.jmir.org">https://www.jmir.org</ext-link>), 11.9.2026. </copyright-statement><copyright-year>2026</copyright-year><license license-type="open-access" xlink:href="https://creativecommons.org/licenses/by/4.0/"><p>This is an open-access article distributed under the terms of the Creative Commons Attribution License (<ext-link ext-link-type="uri" xlink:href="https://creativecommons.org/licenses/by/4.0/">https://creativecommons.org/licenses/by/4.0/</ext-link>), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work, first published in the Journal of Medical Internet Research (ISSN 1438-8871), is properly cited. The complete bibliographic information, a link to the original publication on <ext-link ext-link-type="uri" xlink:href="https://www.jmir.org/">https://www.jmir.org/</ext-link>, as well as this copyright and license information must be included.</p></license><self-uri xlink:type="simple" xlink:href="https://www.jmir.org/2026/1/e93496"/><abstract><sec><title>Background</title><p>Wearable devices are increasingly used for sleep monitoring and as adjunctive treatment. Existing meta-analyses mostly pool composite digital therapies and rarely isolate stand-alone wearables or distinguish between objective and subjective end points. Whether stand-alone wearable interventions improve sleep outcomes in adults with insomnia, and which factors moderate treatment heterogeneity, remains unclear.</p></sec><sec><title>Objective</title><p>This study aims to evaluate the effectiveness of wearable digital interventions on sleep outcomes in adults with insomnia versus control strategies and explore moderators of effectiveness, including device-wearing position, intervention duration, and control type, using meta-regression.</p></sec><sec sec-type="methods"><title>Methods</title><p>This systematic review and meta-analysis was conducted in accordance with the PRISMA (Preferred Reporting Items for Systematic Reviews and Meta&#x2011;Analyses) 2020 statement and the PRISMA-S (Preferred Reporting Items for Systematic Reviews and Meta&#x2011;Analyses Literature Search Extension) guideline. Five electronic databases and clinical trial registries were searched from inception to May 18, 2026. Eligible studies were randomized controlled trials (RCTs) evaluating wearable digital interventions in adults with insomnia compared with sham, waitlist, usual care, or active control conditions and had an intervention duration of at least 1 week. Study screening, data extraction, and risk-of-bias assessment were carried out independently by 2 reviewers. Pooled estimates were calculated using a restricted maximum likelihood random-effects model with the Hartung-Knapp-Sidik-Jonkman correction. Heterogeneity was assessed using the <italic>I</italic>&#x00B2; statistic, and 95% prediction intervals (PIs) were calculated for the primary analyses. The certainty of evidence was rated using the GRADE (Grading of Recommendations, Assessment, Development, and Evaluation) approach.</p></sec><sec sec-type="results"><title>Results</title><p>Sixteen RCTs (N=910) were included. Wearable digital interventions were associated with a significant reduction in objective sleep-onset latency (SOL; mean difference [MD] &#x2212;4.52, 95% CI &#x2212;8.38 to &#x2212;0.67, PI &#x2212;9.52 to 0.47 min) and a significant improvement in subjective sleep efficiency (SE; MD 2.00%, 95% CI 1.90%&#x2010;2.11%, PI 1.85%&#x2010;2.15%). Subjective total sleep time (TST) also showed a significant increase (MD 19.11, 95% CI 2.98&#x2010;35.24, PI &#x2212;16.20 to 54.43 minutes). Meta-regression showed that control type, intervention duration, and device location did not explain the heterogeneity of the insomnia severity index (ISI) (<italic>R</italic><sup>&#x00B2;</sup>=0). Sensitivity analysis confirmed the robustness of pooled ISI estimates, and an Egger test indicated no small-study effects (<italic>P</italic>=.07). Certainty of evidence ranged from moderate to high.</p></sec><sec sec-type="conclusions"><title>Conclusions</title><p>Wearable digital interventions provide selective benefits for objective SOL, subjective SE, and subjective TST in adults with insomnia, with no improvement in overall ISI. Despite statistically significant effects on several sleep parameters, wide PIs, substantial heterogeneity, and limited study numbers indicate preliminary, nonconclusive findings. Wearables should be viewed as affordable adjunctive tools requiring further validation, not substitutes for first-line cognitive behavioral therapy for insomnia. Large-scale, long-term RCTs with standardized protocols and patient-level external validation are required to consolidate the evidence base.</p></sec><sec><title>Trial Registration</title><p>PROSPERO CRD420251038603; https://www.crd.york.ac.uk/PROSPERO/view/CRD420251038603</p></sec></abstract><kwd-group><kwd>insomnia symptoms</kwd><kwd>sleep problems</kwd><kwd>wearable electronic devices</kwd><kwd>digital health</kwd><kwd>meta-analysis</kwd></kwd-group></article-meta></front><body><sec id="s1" sec-type="intro"><title>Introduction</title><p>Insomnia, defined as persistent difficulty in initiating or maintaining sleep accompanied by clinically significant daytime impairment [<xref ref-type="bibr" rid="ref1">1</xref>,<xref ref-type="bibr" rid="ref2">2</xref>], remains one of the most prevalent sleep disorders worldwide. Epidemiological estimates indicate that approximately 10% to 20% of the general adult population meet diagnostic criteria for insomnia disorder [<xref ref-type="bibr" rid="ref1">1</xref>,<xref ref-type="bibr" rid="ref3">3</xref>], with prevalence rising markedly with age, and women being 1.3 to 1.7 times more likely to be affected than men across all age groups [<xref ref-type="bibr" rid="ref4">4</xref>,<xref ref-type="bibr" rid="ref5">5</xref>]. Beyond its immediate impact on sleep quality, insomnia constitutes a major risk factor for various mental disorders, such as depression, anxiety, and alcohol dependence, and is additionally associated with diminished quality of life and increased all-cause mortality [<xref ref-type="bibr" rid="ref4">4</xref>,<xref ref-type="bibr" rid="ref6">6</xref>-<xref ref-type="bibr" rid="ref9">9</xref>], thereby imposing a substantial economic and health care burden on society [<xref ref-type="bibr" rid="ref10">10</xref>]. In the United States alone, the direct costs of insomnia-related medical care, combined with indirect costs from workplace productivity loss, absenteeism, and accidents, have been estimated to exceed US $100 billion annually [<xref ref-type="bibr" rid="ref11">11</xref>,<xref ref-type="bibr" rid="ref12">12</xref>]. In aging societies across East Asia and Europe, this burden is further exacerbated by the disproportionately high prevalence of insomnia among older adults [<xref ref-type="bibr" rid="ref13">13</xref>,<xref ref-type="bibr" rid="ref14">14</xref>] and the corresponding rise in demand for chronic disease management [<xref ref-type="bibr" rid="ref15">15</xref>]. Given this profound public health impact, identifying safe, effective, and scalable interventions for insomnia remains a critical priority for health care systems globally.</p><p>The management of insomnia encompasses psychological, behavioral, pharmacological, and complementary approaches [<xref ref-type="bibr" rid="ref3">3</xref>,<xref ref-type="bibr" rid="ref9">9</xref>]. Among these, cognitive behavioral therapy for insomnia (CBT-I) is recommended as first-line treatment on the basis of robust empirical evidence [<xref ref-type="bibr" rid="ref2">2</xref>,<xref ref-type="bibr" rid="ref5">5</xref>]. However, its widespread implementation is severely constrained. The global shortage of trained CBT-I therapists [<xref ref-type="bibr" rid="ref16">16</xref>], together with high per-session costs (which average US $260 in the United States [<xref ref-type="bibr" rid="ref17">17</xref>]) and marked geographic disparities in service availability [<xref ref-type="bibr" rid="ref17">17</xref>], means that the vast majority of patients with insomnia rarely receive guideline-recommended behavioral treatment [<xref ref-type="bibr" rid="ref2">2</xref>,<xref ref-type="bibr" rid="ref3">3</xref>,<xref ref-type="bibr" rid="ref5">5</xref>]. Pharmacological treatments, including benzodiazepine receptor agonists and Z-drugs, provide short-term symptomatic relief but entail substantial risks with long-term use [<xref ref-type="bibr" rid="ref18">18</xref>], including physical dependence, tolerance, rebound insomnia on discontinuation, cognitive impairment, next-day sedation, and increased fall risk, especially in older adults [<xref ref-type="bibr" rid="ref19">19</xref>]. Consequently, clinical guidelines universally recommend limiting hypnotic use to the lowest effective dose and the shortest necessary duration, with pharmacotherapy generally restricted to short&#x2011;term use of no more than 4 to 5 weeks [<xref ref-type="bibr" rid="ref20">20</xref>]. The persistent gap between high treatment demand and limited access to evidence-based nonpharmacological therapies highlights the need for scalable alternatives that do not require the infrastructure and workforce associated with traditional CBT-I.</p><p>In recent years, digital therapeutics, particularly wearable devices, have emerged as a rapidly advancing frontier in sleep medicine [<xref ref-type="bibr" rid="ref21">21</xref>-<xref ref-type="bibr" rid="ref23">23</xref>]. Adoption of wearable sleep technology, including smartwatches, wristbands, head-mounted electroencephalography (EEG) systems, and therapeutic filtered-light glasses, has grown substantially, driven by increasing public awareness of sleep health and advances in miniaturized sensing technology [<xref ref-type="bibr" rid="ref24">24</xref>,<xref ref-type="bibr" rid="ref25">25</xref>]. These devices enable continuous, real-time physiological monitoring (eg, heart rate variability, actigraphy [<xref ref-type="bibr" rid="ref26">26</xref>]) and can provide active therapeutic functions such as acoustic stimulation, transcranial electrical stimulation, and biofeedback-based sleep retraining [<xref ref-type="bibr" rid="ref2">2</xref>,<xref ref-type="bibr" rid="ref26">26</xref>-<xref ref-type="bibr" rid="ref28">28</xref>]. Nevertheless, the available synthesized evidence on the efficacy of stand-alone wearable devices for insomnia remains limited.</p><p>Several earlier systematic reviews have sought to synthesize evidence in this field. For instance, Jung et al [<xref ref-type="bibr" rid="ref8">8</xref>] examined mobile apps for insomnia but did not specifically focus on wearable devices used as stand-alone interventions. Bai et al [<xref ref-type="bibr" rid="ref29">29</xref>] and Hwang et al [<xref ref-type="bibr" rid="ref30">30</xref>] assessed digital CBT-I programs rather than the wearable hardware itself. Baron et al [<xref ref-type="bibr" rid="ref31">31</xref>] and Glazer Baron et al [<xref ref-type="bibr" rid="ref32">32</xref>] centered their reviews on measurement rather than on therapeutic efficacy. Lai et al [<xref ref-type="bibr" rid="ref33">33</xref>] reviewed wearable-delivered interventions but pooled heterogeneous populations and did not include any studies published after December 2021. Critically, however, few prior reviews have systematically distinguished between objectively measured sleep parameters and patient-reported subjective sleep outcomes.</p><p>Critically, this review was designed to address several knowledge gaps that were not fully addressed in previous meta-analyses. First, rather than aggregating composite digital therapies (eg, wearables combined with app-guided psychotherapy), we focused exclusively on stand-alone wearable interventions to isolate their pure therapeutic effect. Second, we explicitly stratified outcomes into objective sleep parameters (measured by actigraphy or polysomnography) and subjective patient-reported outcomes, given that these 2 domains frequently yield discrepant findings in insomnia research and carry distinct clinical implications. Third, we performed targeted meta-regression to quantitatively investigate sources of heterogeneity in insomnia severity scores, an approach not systematically applied in prior reviews. Fourth, we used the confidence distribution approach proposed by Nagashima et al [<xref ref-type="bibr" rid="ref34">34</xref>] to compute prediction intervals (PIs), thereby going beyond average pooled estimates to provide a more reliable estimate of the true effect distribution across different clinical settings and populations.</p><p>Taken together, the existing literature remains inadequate, owing to fragmentation across technologies, heterogeneity in the conceptualization and measurement of sleep outcomes, and a scarcity of evaluations that isolate the stand-alone effect of wearable hardware while simultaneously distinguishing objective end points from subjective ones and exploring sources of heterogeneity. This review addresses these limitations by concentrating exclusively on stand-alone wearable devices, categorizing outcomes according to objective and subjective measures, and using more conservative statistical methods, including the Hartung-Knapp-Sidik-Jonkman (HKSJ) approach [<xref ref-type="bibr" rid="ref35">35</xref>] and Nagashima-corrected PIs [<xref ref-type="bibr" rid="ref34">34</xref>]. Accordingly, the aim of this systematic review and meta-analysis was to evaluate the therapeutic efficacy of stand-alone wearable digital interventions on objective and subjective sleep outcomes relative to various control conditions in adults with insomnia.</p></sec><sec id="s2" sec-type="methods"><title>Methods</title><sec id="s2-1"><title>Protocol and Guidance</title><p>This systematic review and meta-analysis was conducted in accordance with the PRISMA (Preferred Reporting Items for Systematic Reviews and Meta-Analyses) 2020 statement [<xref ref-type="bibr" rid="ref36">36</xref>] and was registered prospectively with PROSPERO (International Prospective Register of Systematic Reviews). The PRISMA 2020 expanded checklist is provided in <xref ref-type="supplementary-material" rid="app2">Checklist 1</xref>. No deviations from the registered protocol occurred during the study.</p></sec><sec id="s2-2"><title>Eligibility Criteria</title><p>We included randomized controlled trials (RCTs) [<xref ref-type="bibr" rid="ref37">37</xref>] that used wearable-delivered interventions for adults with insomnia. Eligible participants were adults with an insomnia severity index (ISI) score &#x003E;7 or those meeting the diagnostic criteria for insomnia disorder as defined by established international classification systems (eg, the <italic>Diagnostic and Statistical Manual of Mental Disorders</italic> or the International Classification of Sleep Disorders). Wearable digital devices (eg, smartwatches, wristbands, and rings) were defined as devices equipped with sleep monitoring as well as active therapeutic functions (eg, acoustic stimulation, filtered light glasses). The intervention was required to be compared against a control condition such as usual care, a sham device, or a waitlist control.</p><p>Exclusion criteria were as follows: (1) acute or critical illnesses in participants, (2) intervention duration of less than 1 week, (3) unavailability of full text of the article, and (4) duplicate publications or studies with overlapping data.</p></sec><sec id="s2-3"><title>Information Sources</title><p>We searched the following electronic databases from inception to April 30, 2025, without language restrictions: PubMed, Embase, Web of Science, PsycINFO, and the Cochrane Central Register of Controlled Trials. The search was updated on May 18, 2026, to capture newly published studies. The full search strategies for each database are provided in <xref ref-type="supplementary-material" rid="app1">Multimedia Appendix 1</xref>.</p></sec><sec id="s2-4"><title>Search Strategy</title><p>The search was reported according to the PRISMA-S (Preferred Reporting Items for Systematic Reviews and Meta-Analyses literature search extension) guideline [<xref ref-type="bibr" rid="ref38">38</xref>]. We searched PubMed, Embase, Web of Science, PsycINFO, and the Cochrane Library from inception to April 30, 2025 (updated May 18, 2026). The search combined controlled vocabulary (MeSH in PubMed/Cochrane, Emtree in Embase) and free-text terms for 3 domains: wearable devices (eg, &#x201C;wearable electronic devices,&#x201D; &#x201C;actigraphy,&#x201D; &#x201C;smartwatch&#x201D;), insomnia (eg, &#x201C;insomnia,&#x201D; &#x201C;sleep initiation and maintenance disorders&#x201D;), and RCTs (eg, &#x201C;randomized controlled trial,&#x201D; &#x201C;RCT&#x201D;). No language or date restrictions were applied. The detailed search strategies for each database are provided in <xref ref-type="supplementary-material" rid="app1">Multimedia Appendix 1</xref>. The PRISMA-S checklist is provided in <xref ref-type="supplementary-material" rid="app3">Checklist 2</xref>. Backward and forward citation searches of included studies were also performed.</p><p>No multidatabase searching, independent registry searches, online browsing, contacting authors, use of published search filters, adaptations from prior reviews, or formal peer review were performed. Each database was searched separately.</p></sec><sec id="s2-5"><title>Selection Process</title><p>Two independent reviewers (WZ and MC) screened the titles, abstracts, and full texts of all retrieved articles. Studies assessed as potentially relevant or unclear at the title and abstract stage were obtained in full text and reevaluated. Any disagreements between the reviewers were resolved through discussion or by consultation with a third investigator (YG).</p></sec><sec id="s2-6"><title>Data Collection Process</title><p>Data were extracted independently by 2 reviewers (WZ and MC) using a standardized data extraction form. Any disagreements were resolved through discussion or consultation with a third reviewer (YG). When data were missing or unclear, we contacted the corresponding authors of the original studies via email. No automation tools were used in the data collection process.</p></sec><sec id="s2-7"><title>Data Items</title><p>For each included study, we extracted the primary outcome (ISI), secondary outcomes (objective sleep parameters: total sleep time [TST], sleep-onset latency [SOL], wake after sleep onset [WASO], sleep efficiency [SE]; and subjective sleep parameters: Pittsburgh Sleep Quality Index [PSQI], subjective TST, SOL, WASO, SE, Epworth Sleepiness Scale [ESS], and single-item sleep quality), and other variables (first author, year, country, design, participant characteristics, intervention details, comparator, attrition, intention-to-treat or missing data methods, trial registration, and funding).</p></sec><sec id="s2-8"><title>Study Risk-of-Bias Assessment</title><p>The Cochrane Risk-of-Bias 2.0 (RoB 2.0) tool for randomized trials was used to evaluate the methodological quality of the included studies across 5 bias domains. Assessments were carried out independently by 2 reviewers (WZ and MC).</p></sec><sec id="s2-9"><title>Effect Measures</title><p>For continuous outcomes (ISI, TST, SOL, WASO, SE, ESS, PSQI, and sleep quality), the effect measure was the mean difference (MD) with a 95% CI. When different scales were used for the same construct (eg, different sleep quality measures), we planned to use the standardized mean difference (SMD; Hedges <italic>g</italic>). However, all included studies reported outcomes on the same or directly convertible metrics, so MD was used throughout. All included trials used identical measurement units for each sleep parameter (eg, minutes for SOL, TST, and WASO and percentages for SE), enabling direct pooling with MD rather than SMD. Between-study differences in absolute values reflect clinical and demographic heterogeneity in study populations rather than any inconsistency in outcome scaling.</p></sec><sec id="s2-10"><title>Synthesis Methods</title><p>Studies were grouped by outcome domain (ISI, objective sleep parameters, and subjective sleep parameters). Postintervention means and SDs were extracted; when only change scores were reported, the postintervention SD was calculated using a correlation coefficient of 0.5 [<xref ref-type="bibr" rid="ref39">39</xref>]. Meta-analyses were performed using a random-effects model with the HKSJ correction (metafor package in R [R Foundation for Statistical Computing]) to reduce the risk of inflated type I errors [<xref ref-type="bibr" rid="ref36">36</xref>,<xref ref-type="bibr" rid="ref40">40</xref>], with heterogeneity assessed using <italic>I</italic>&#x00B2; statistics and <italic>Q</italic> tests. Nagashima-corrected 95% PIs [<xref ref-type="bibr" rid="ref34">34</xref>] were calculated for all pooled outcomes and displayed in forest plots. To explore heterogeneity, meta-regression was conducted only for ISI with 3 prespecified moderators (control type, intervention duration, and device-wearing position). Sensitivity analyses included leave-one-out analysis for ISI and rerunning all meta-analyses after the updated literature search.</p></sec><sec id="s2-11"><title>Reporting Bias Assessment</title><p>Funnel plots and Egger regression test were used to examine small-study effects (not publication bias directly). For outcomes with fewer than 10 studies, these tests were not performed due to limited statistical power. No trim-and-fill or other adjustment methods were applied. No other reporting bias assessments were conducted.</p></sec><sec id="s2-12"><title>Certainty Assessment</title><p>The certainty of evidence for each outcome was evaluated using the GRADE (Grading of Recommendations, Assessment, Development, and Evaluation) approach. Two reviewers (WZ and MC) independently rated the evidence across 5 domains: risk of bias, inconsistency, indirectness, imprecision, and publication bias. Disagreements were resolved by consensus. The overall certainty was graded as high, moderate, low, or very low. Outcomes with fewer than 3 studies were not graded.</p></sec></sec><sec id="s3" sec-type="results"><title>Results</title><sec id="s3-1"><title>Study Selection</title><p>Of the 3815 records identified through database searching, 3799 were excluded after the removal of duplicates and the exclusion of irrelevant studies. All studies included independent participants, and no double-counting occurred. We updated the literature search on May 18, 2026, adding 2 new RCTs, and conducted a reanalysis of the statistics. The remaining 16 RCTs [<xref ref-type="bibr" rid="ref41">41</xref>-<xref ref-type="bibr" rid="ref56">56</xref>] met the eligibility criteria and were included in the final analysis. The study selection process is summarized in the PRISMA flow diagram (<xref ref-type="fig" rid="figure1">Figure 1</xref>).</p><fig position="float" id="figure1"><label>Figure 1.</label><caption><p>Flowchart for study selection. RCT: randomized controlled trial.</p></caption><graphic alt-version="no" mimetype="image" position="float" xlink:type="simple" xlink:href="jmir_v28i1e93496_fig01.png"/></fig></sec><sec id="s3-2"><title>Study Characteristics</title><p>Most studies reported low-to-moderate attrition rates. However, Aji et al [<xref ref-type="bibr" rid="ref42">42</xref>] reported a high dropout rate (40/91, 44.0% among app initiators), with significantly more dropouts in the control group than in the intervention group, which the authors attributed to the fully digital, unsupervised design, and lack of face-to-face contact. Zabrecky et al [<xref ref-type="bibr" rid="ref56">56</xref>] reported a dropout rate of 23.1% (9/39), mainly due to scheduling conflicts (n=4), inability to tolerate MRI scanning (n=2), and unspecified reasons (n=3), with no separate reporting by randomization group. For the remaining 8 studies, attrition rates ranged from 0% to 16%, and reasons for dropout were mostly unrelated to the intervention.</p><p>Among the 16 included RCTs, a total of 910 participants were enrolled across all studies, with sample sizes ranging from 14 to 152 per trial. A summary of the characteristics of the included studies is presented in <xref ref-type="table" rid="table1">Table 1</xref>. The publication years of the included studies spanned from 2017 to 2026; 11 [<xref ref-type="bibr" rid="ref41">41</xref>-<xref ref-type="bibr" rid="ref43">43</xref>,<xref ref-type="bibr" rid="ref47">47</xref>-<xref ref-type="bibr" rid="ref52">52</xref>,<xref ref-type="bibr" rid="ref54">54</xref>,<xref ref-type="bibr" rid="ref56">56</xref>] reported the ISI, 9 [<xref ref-type="bibr" rid="ref45">45</xref>,<xref ref-type="bibr" rid="ref47">47</xref>-<xref ref-type="bibr" rid="ref52">52</xref>,<xref ref-type="bibr" rid="ref54">54</xref>-<xref ref-type="bibr" rid="ref56">56</xref>] reported TST, and 12 [<xref ref-type="bibr" rid="ref41">41</xref>,<xref ref-type="bibr" rid="ref43">43</xref>,<xref ref-type="bibr" rid="ref45">45</xref>-<xref ref-type="bibr" rid="ref52">52</xref>,<xref ref-type="bibr" rid="ref54">54</xref>,<xref ref-type="bibr" rid="ref55">55</xref>] contained objective sleep data, while 10 [<xref ref-type="bibr" rid="ref41">41</xref>-<xref ref-type="bibr" rid="ref43">43</xref>,<xref ref-type="bibr" rid="ref46">46</xref>-<xref ref-type="bibr" rid="ref49">49</xref>,<xref ref-type="bibr" rid="ref51">51</xref>,<xref ref-type="bibr" rid="ref52">52</xref>,<xref ref-type="bibr" rid="ref55">55</xref>] included subjective sleep outcomes. The comparators consisted of sham interventions [<xref ref-type="bibr" rid="ref41">41</xref>,<xref ref-type="bibr" rid="ref43">43</xref>-<xref ref-type="bibr" rid="ref49">49</xref>,<xref ref-type="bibr" rid="ref52">52</xref>,<xref ref-type="bibr" rid="ref53">53</xref>,<xref ref-type="bibr" rid="ref55">55</xref>], waitlist [<xref ref-type="bibr" rid="ref50">50</xref>,<xref ref-type="bibr" rid="ref56">56</xref>], usual care [<xref ref-type="bibr" rid="ref42">42</xref>,<xref ref-type="bibr" rid="ref51">51</xref>], and active control [<xref ref-type="bibr" rid="ref54">54</xref>]. Interventions were delivered via wearable devices: head-mounted devices [<xref ref-type="bibr" rid="ref41">41</xref>,<xref ref-type="bibr" rid="ref44">44</xref>-<xref ref-type="bibr" rid="ref46">46</xref>,<xref ref-type="bibr" rid="ref48">48</xref>,<xref ref-type="bibr" rid="ref50">50</xref>,<xref ref-type="bibr" rid="ref52">52</xref>,<xref ref-type="bibr" rid="ref54">54</xref>], therapeutic filtered light glasses [<xref ref-type="bibr" rid="ref47">47</xref>,<xref ref-type="bibr" rid="ref49">49</xref>], neck-worn devices [<xref ref-type="bibr" rid="ref43">43</xref>,<xref ref-type="bibr" rid="ref53">53</xref>], ear-worn devices [<xref ref-type="bibr" rid="ref55">55</xref>], and wristbands [<xref ref-type="bibr" rid="ref42">42</xref>,<xref ref-type="bibr" rid="ref51">51</xref>,<xref ref-type="bibr" rid="ref56">56</xref>]. The intervention duration ranged from 2 weeks to 3 months. For all outcomes, posttreatment values were extracted to calculate effect sizes, as detailed in the &#x201C;Methods&#x201D; section.</p><table-wrap id="t1" position="float"><label>Table 1.</label><caption><p>Characteristics of the included studies.</p></caption><table id="table1" frame="hsides" rules="groups"><thead><tr><td align="left" valign="bottom">Author,<break/>year, country</td><td align="left" valign="bottom">Design</td><td align="left" valign="bottom">Population</td><td align="left" valign="bottom">Sample<break/>size</td><td align="left" valign="bottom">Intervention</td><td align="left" valign="bottom">Control</td><td align="left" valign="bottom">Outcomes measures</td><td align="left" valign="bottom">Attrition (%)</td><td align="left" valign="bottom">ITT<sup><xref ref-type="table-fn" rid="table1fn1">a</xref></sup>/MDM<sup><xref ref-type="table-fn" rid="table1fn2">b</xref></sup></td><td align="left" valign="bottom">Protocol/registration</td><td align="left" valign="bottom">Grant</td></tr></thead><tbody><tr><td align="left" valign="top">Aji et al [<xref ref-type="bibr" rid="ref42">42</xref>], 2022, Australia</td><td align="left" valign="top">2-arm RCT<sup><xref ref-type="table-fn" rid="table1fn3">c</xref></sup></td><td align="left" valign="top">ISI<sup><xref ref-type="table-fn" rid="table1fn4">d</xref></sup>&#x2265;15 and PSQI<sup><xref ref-type="table-fn" rid="table1fn5">e</xref></sup> global&#x003E;5 (42.6&#x00B1;10.7)</td><td align="left" valign="top">T<sup><xref ref-type="table-fn" rid="table1fn6">f</xref></sup>: 128<break/>I<sup><xref ref-type="table-fn" rid="table1fn7">g</xref></sup>: 62<break/>C<sup><xref ref-type="table-fn" rid="table1fn8">h</xref></sup>: 66</td><td align="left" valign="top">Wearable technology (Fitbit Charge 2)</td><td align="left" valign="top">dBTi<sup><xref ref-type="table-fn" rid="table1fn9">i</xref></sup> only</td><td align="left" valign="top">ISI, daytime sleepiness (ESS<sup><xref ref-type="table-fn" rid="table1fn10">j</xref></sup>)</td><td align="left" valign="top">44</td><td align="left" valign="top">No/No</td><td align="left" valign="top">No/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Anderson et al [<xref ref-type="bibr" rid="ref43">43</xref>], 2025, United States</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">ISI&#x2265;15 (40.4&#x00B1;12.1)</td><td align="left" valign="top">T: 58<break/>I: 27<break/>C: 31</td><td align="left" valign="top">Evolv28 (wearable neckband device)</td><td align="left" valign="top">Sham device</td><td align="left" valign="top">Primary: ISI<break/>Secondary: sleep duration, WASO<sup><xref ref-type="table-fn" rid="table1fn11">k</xref></sup> (min), SE<sup><xref ref-type="table-fn" rid="table1fn12">l</xref></sup> (%)<break/>Objective: (actigraphy) TST<sup><xref ref-type="table-fn" rid="table1fn13">m</xref></sup> (min), SE (%), WASO (min)</td><td align="left" valign="top">8.47</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Bressler et al [<xref ref-type="bibr" rid="ref44">44</xref>], 2023, United States</td><td align="left" valign="top">RCT</td><td align="left" valign="top">ISI&#x2265;21 and PSQI global&#x003E;5 (33.0&#x00B1;6.6)</td><td align="left" valign="top">T: 48<break/>I: 24<break/>C: 24</td><td align="left" valign="top">Elemind Neuromodulation Device<break/>(a wearable EEG<sup><xref ref-type="table-fn" rid="table1fn14">n</xref></sup>)</td><td align="left" valign="top">Sham device</td><td align="left" valign="top">Sleep physiology metrics: sleep stage scoring, SOL<sup><xref ref-type="table-fn" rid="table1fn15">o</xref></sup>, phase tracking accuracy of alpha oscillations (8&#x2010;12 Hz)<break/>Subjective: (sleep diary) bedtime, wake time, sleep quality</td><td align="left" valign="top">0</td><td align="left" valign="top">No/No</td><td align="left" valign="top">No/No</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Chen et al [<xref ref-type="bibr" rid="ref45">45</xref>], 2026, China</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">PSQI&#x003E;7 (I: 20.85&#x00B1;2.2; C: 20.44&#x00B1;1.7)</td><td align="left" valign="top">T: 20<break/>I: 10<break/>C: 10</td><td align="left" valign="top">cTBS<sup><xref ref-type="table-fn" rid="table1fn16">p</xref></sup></td><td align="left" valign="top">Sham device</td><td align="left" valign="top">Objective (actigraphy): SOL, TST, TA<sup><xref ref-type="table-fn" rid="table1fn17">q</xref></sup>, SFI<sup><xref ref-type="table-fn" rid="table1fn18">r</xref></sup></td><td align="left" valign="top">0</td><td align="left" valign="top">Yes/No</td><td align="left" valign="top">No/No</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Curry et al [<xref ref-type="bibr" rid="ref46">46</xref>], 2024, United Kingdom</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">ISI&#x2265;15 (40.8&#x00B1;13.5)</td><td align="left" valign="top">T: 126<break/>I: 61<break/>C: 65</td><td align="left" valign="top">Modius Sleep device</td><td align="left" valign="top">Sham device</td><td align="left" valign="top">Primary: change in ISI score<break/>Secondary: PSQI, RAND 36-Item Short Form Survey, caffeine diaries</td><td align="left" valign="top">15.65</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Esaki et al [<xref ref-type="bibr" rid="ref47">47</xref>], 2020, Japan</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">Bipolar disorder ISI&#x2265;8 (I: 44.1&#x00B1;11.8; C: 41.1&#x00B1;10.4)</td><td align="left" valign="top">T: 43<break/>I: 21<break/>C: 22</td><td align="left" valign="top">Blue-blocking orange glasses</td><td align="left" valign="top">Clear placebo glasses</td><td align="left" valign="top">Objective (actigraphy): SE, SOL, WASO, TST<break/>Subjective: VAS<sup><xref ref-type="table-fn" rid="table1fn19">s</xref></sup>, ISI, MEQ<sup><xref ref-type="table-fn" rid="table1fn20">t</xref></sup></td><td align="left" valign="top">14.0</td><td align="left" valign="top">Yes/No</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">He et al [<xref ref-type="bibr" rid="ref48">48</xref>], 2024, China</td><td align="left" valign="top">4-arm RCT</td><td align="left" valign="top">ISI&#x003E;7 and PSQI global &#x003E;5 (67.68&#x00B1;4.98)</td><td align="left" valign="top">T: 152<break/>I1: 38<break/>I2: 38<break/>I3: 38<break/>C: 38</td><td align="left" valign="top">I1: TC<sup><xref ref-type="table-fn" rid="table1fn21">u</xref></sup>+active rTMS<sup><xref ref-type="table-fn" rid="table1fn22">v</xref></sup><break/>I2: TC+sham rTMS<break/>I3: TC alone</td><td align="left" valign="top">Low-intensity PE</td><td align="left" valign="top">Primary: ISI<break/>Secondary: Objective (actigraphy): TST (min), SOL (min), SE (%), WASO (min), number of awakenings, average wake time per awakening. Subjective (sleep diary): daytime sleepiness: Chinese version of the ESS</td><td align="left" valign="top">9.21</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Jank&#x016F; et al [<xref ref-type="bibr" rid="ref49">49</xref>], 2020, Czech Republic</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">Diagnosed with insomnia<break/>(48.1&#x00B1;16.1)</td><td align="left" valign="top">T: 30<break/>I: 15<break/>C: 15</td><td align="left" valign="top">UVEX S1933X orange glasses</td><td align="left" valign="top">UVEX S1900 clear glasses</td><td align="left" valign="top">Subjective (sleep diaries): SOL (min), TST (min), WASO (min), SE (%), SQ<sup><xref ref-type="table-fn" rid="table1fn23">w</xref></sup><break/>Objective (actigraphy): SOL (min), TST (min), WASO (min), SE (%)</td><td align="left" valign="top">14.29</td><td align="left" valign="top">No/No</td><td align="left" valign="top">No/No</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Jeon and Choi [<xref ref-type="bibr" rid="ref50">50</xref>], 2017, South Korea</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">ISI&#x2265;15 and PSQI global &#x2265;5<break/>(I: 23.5&#x00B1;1.73; C: 25.6&#x00B1;2.88)</td><td align="left" valign="top">T: 14<break/>I: 5<break/>C: 9</td><td align="left" valign="top">Neurofeedback therapy<break/>(Procomp 5)</td><td align="left" valign="top">Waiting only</td><td align="left" valign="top">Objective: TST (min), SL<sup><xref ref-type="table-fn" rid="table1fn24">x</xref></sup> (min), SE (%) (Smart Wearable Device)<break/>Subjective: insomnia symptom severity (ISI), PSQI, ESS, Presleep Arousal Scale (sleep diary)</td><td align="left" valign="top">0</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">No/No</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Kang et al [<xref ref-type="bibr" rid="ref51">51</xref>], 2017, South Korea</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">Insomnia disorder (45.1&#x00B1;9.8)</td><td align="left" valign="top">T: 19<break/>I: 10<break/>C: 9</td><td align="left" valign="top">Wearable sleep tracker (Fitbit Charge HR)</td><td align="left" valign="top">CBT-I<sup><xref ref-type="table-fn" rid="table1fn25">y</xref></sup> and app only</td><td align="left" valign="top">Objective: SE (%) (actigraphy)<break/>Subjective: sleep quality (PSQI), insomnia symptom severity (ISI), SE (%) (PSQI), TST (min), SL (min), TIB<sup><xref ref-type="table-fn" rid="table1fn26">z</xref></sup> (min), SE (%) (sleep diary)</td><td align="left" valign="top">0</td><td align="left" valign="top">No/No</td><td align="left" valign="top">No/No</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Kennedy et al [<xref ref-type="bibr" rid="ref53">53</xref>], 2023, United States</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">ISI&#x2265;8 (51.18&#x00B1;10.50)</td><td align="left" valign="top">T: 30<break/>I: 15<break/>C: 15</td><td align="left" valign="top">CeraZ Technologies LLC</td><td align="left" valign="top">Sham device</td><td align="left" valign="top">Objective (oura ring): SE (%), TST (min), TIB (min), SOL (min)<break/>Subjective (sleep diaries): SOL (min), sleep quality, Karolinska Sleepiness Scale scores</td><td align="left" valign="top">0</td><td align="left" valign="top">No/No</td><td align="left" valign="top">No/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Lee et al [<xref ref-type="bibr" rid="ref41">41</xref>], 2024, Korea</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">ISI&#x2265;8 BDI-II=20 (I: 49.40&#x00B1;11.76; C: 48.67&#x00B1;12.90)</td><td align="left" valign="top">T: 38<break/>I: 20<break/>C: 18</td><td align="left" valign="top">MAVE device</td><td align="left" valign="top">Sham device</td><td align="left" valign="top">Subjective: PSS, BDI-II<sup><xref ref-type="table-fn" rid="table1fn27">aa</xref></sup>, ISI, PSQI, STAI<sup><xref ref-type="table-fn" rid="table1fn28">ab</xref></sup>, WHOQOL-BREF<sup><xref ref-type="table-fn" rid="table1fn29">ac</xref></sup><break/>Objective: qEEG<sup><xref ref-type="table-fn" rid="table1fn30">ad</xref></sup>, ACTH, cortisol, BDNF<sup><xref ref-type="table-fn" rid="table1fn31">ae</xref></sup></td><td align="left" valign="top">16.33</td><td align="left" valign="top">No/No</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Liu et al [<xref ref-type="bibr" rid="ref52">52</xref>], 2025, China</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">Sleep disorders, experiencing MCI<sup><xref ref-type="table-fn" rid="table1fn32">af</xref></sup> without dementia (67.9&#x00B1;4.6)</td><td align="left" valign="top">T: 110<break/>I: 55<break/>C: 55</td><td align="left" valign="top">rTMS+TC</td><td align="left" valign="top">Sham rTMS+ TC</td><td align="left" valign="top">Objective: (actigraphy) SE, SOL, WASO, TST<break/>Subjective: PSQI, ESS, HAMA<sup><xref ref-type="table-fn" rid="table1fn33">ag</xref></sup>, HAMD<sup><xref ref-type="table-fn" rid="table1fn34">ah</xref></sup>, MoCA<sup><xref ref-type="table-fn" rid="table1fn35">ai</xref></sup></td><td align="left" valign="top">6.4</td><td align="left" valign="top">Yes/No</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Simons et al [<xref ref-type="bibr" rid="ref54">54</xref>], 2024, United States</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">ISI&#x2265;8 (MI<sup><xref ref-type="table-fn" rid="table1fn36">aj</xref></sup>: 52; MC<sup><xref ref-type="table-fn" rid="table1fn37">ak</xref></sup>: 50.5)</td><td align="left" valign="top">T: 24<break/>I: 12<break/>C:12</td><td align="left" valign="top">SDR-tES<sup><xref ref-type="table-fn" rid="table1fn38">al</xref></sup> (wearable device)</td><td align="left" valign="top">Active control</td><td align="left" valign="top">Primary: SOL<break/>Secondary: TST, WASO, ISI, SE, STAI (state subform)</td><td align="left" valign="top">0</td><td align="left" valign="top">No/Yes</td><td align="left" valign="top">No/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Yeom et al [<xref ref-type="bibr" rid="ref55">55</xref>], 2025, South Korea</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">ICSD-3<sup><xref ref-type="table-fn" rid="table1fn39">am</xref></sup>, PSQI&#x2265;5<break/>(I: 31.9&#x00B1;12.3; C: 29.4&#x00B1;8.0)</td><td align="left" valign="top">T: 40<break/>I: 20<break/>C: 20</td><td align="left" valign="top">Transcutaneous auricular vagus nerve stimulation</td><td align="left" valign="top">Sham device</td><td align="left" valign="top">Objective: (Fitbit) TST<break/>Subjective: PSQI, ISI, WHOQOL-BREF</td><td align="left" valign="top">2.5</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes/Yes</td><td align="left" valign="top">Yes</td></tr><tr><td align="left" valign="top">Zabrecky et al [<xref ref-type="bibr" rid="ref56">56</xref>], 2020, United States</td><td align="left" valign="top">2-arm RCT</td><td align="left" valign="top">Insomnia disorder<break/>(I: 43.3&#x00B1;19.6; C: 40.8&#x00B1;1.6)</td><td align="left" valign="top">T: 30<break/>I: 19<break/>C: 11</td><td align="left" valign="top">VibrAcoustic Wellness System</td><td align="left" valign="top">Waiting only</td><td align="left" valign="top">Objective: (actigraphy) neurological assessment: resting state functional magnetic resonance imaging<break/>Subjective: ISI</td><td align="left" valign="top">23.08</td><td align="left" valign="top">No/No</td><td align="left" valign="top">No/No</td><td align="left" valign="top">Yes</td></tr></tbody></table><table-wrap-foot><fn id="table1fn1"><p><sup>a</sup>ITT: intention-to-treat analysis.</p></fn><fn id="table1fn2"><p><sup>b</sup>MDM: missing data management.</p></fn><fn id="table1fn3"><p><sup>c</sup>RCT: randomized controlled trial.</p></fn><fn id="table1fn4"><p><sup>d</sup>ISI: insomnia severity index.</p></fn><fn id="table1fn5"><p><sup>e</sup>PSQI: Pittsburgh Sleep Quality Index.</p></fn><fn id="table1fn6"><p><sup>f</sup>T: total.</p></fn><fn id="table1fn7"><p><sup>g</sup>I: intervention.</p></fn><fn id="table1fn8"><p><sup>h</sup>C: control.</p></fn><fn id="table1fn9"><p><sup>i</sup>dBTi: digital behavioral therapy for insomnia.</p></fn><fn id="table1fn10"><p><sup>j</sup>ESS: Epworth Sleepiness Scale.</p></fn><fn id="table1fn11"><p><sup>k</sup>WASO: wake after sleep onset.</p></fn><fn id="table1fn12"><p><sup>l</sup>SE: sleep efficiency.</p></fn><fn id="table1fn13"><p><sup>m</sup>TST: total sleep time.</p></fn><fn id="table1fn14"><p><sup>n</sup>EEG: electroencephalography.</p></fn><fn id="table1fn15"><p><sup>o</sup>SOL: sleep-onset latency.</p></fn><fn id="table1fn16"><p><sup>p</sup>cTBS: continuous theta burst stimulation.</p></fn><fn id="table1fn17"><p><sup>q</sup>TA: time awake.</p></fn><fn id="table1fn18"><p><sup>r</sup>SFI: sleep fragmentation index.</p></fn><fn id="table1fn19"><p><sup>s</sup>VAS: visual analog scale.</p></fn><fn id="table1fn20"><p><sup>t</sup>MEQ: Morningness&#x2013;Eveningness Questionnaire.</p></fn><fn id="table1fn21"><p><sup>u</sup>TC: Tai Chi.</p></fn><fn id="table1fn22"><p><sup>v</sup>rTMS: repetitive transcranial magnetic stimulation.</p></fn><fn id="table1fn23"><p><sup>w</sup>SQ: sleep quality.</p></fn><fn id="table1fn24"><p><sup>x</sup>SL: sleep latency.</p></fn><fn id="table1fn25"><p><sup>y</sup>CBT-I: cognitive behavioral therapy for insomnia.</p></fn><fn id="table1fn26"><p><sup>z</sup>TIB: time in bed.</p></fn><fn id="table1fn27"><p><sup>aa</sup>BDI-II: Beck Depression Inventory-II.</p></fn><fn id="table1fn28"><p><sup>ab</sup>STAI: State Trait Anxiety Index.</p></fn><fn id="table1fn29"><p><sup>ac</sup>WHOQOL-BREF: World Health Organization Quality of Life&#x2011;BREF.</p></fn><fn id="table1fn30"><p><sup>ad</sup>qEEG: Quantitative electroencephalography.</p></fn><fn id="table1fn31"><p><sup>ae</sup>BDNF: brain&#x2011;derived neurotrophic factor.</p></fn><fn id="table1fn32"><p><sup>af</sup>MCI: mild cognitive impairment.</p></fn><fn id="table1fn33"><p><sup>ag</sup>HAMA: Hamilton Anxiety Rating Scale.</p></fn><fn id="table1fn34"><p><sup>ah</sup>HAMD: Hamilton Depression Rating Scale.</p></fn><fn id="table1fn35"><p><sup>ai</sup>MoCA: Montreal Cognitive Assessment.</p></fn><fn id="table1fn36"><p><sup>aj</sup>MI: median intervention.</p></fn><fn id="table1fn37"><p><sup>ak</sup>MC: median control.</p></fn><fn id="table1fn38"><p><sup>al</sup>SDR-tES: short duration repetitive transcranial electric stimulation.</p></fn><fn id="table1fn39"><p><sup>am</sup>ICSD-3: International Classification of Sleep Disorders&#x2011;Third Edition.</p></fn></table-wrap-foot></table-wrap></sec><sec id="s3-3"><title>Results of Syntheses</title></sec><sec id="s3-4"><title>ISI</title><p>ISI scores were reported in 10 studies. The pooled random-effects estimate, using the HKSJ correction, showed no significant reduction in ISI scores (MD &#x2212;1.82, 95% CI &#x2212;4.33 to 0.69, PI &#x2212;8.95 to 5.31), with substantial between-study heterogeneity (<italic>I</italic>&#x00B2;=73.2%; <xref ref-type="fig" rid="figure2">Figure 2</xref>).</p><fig position="float" id="figure2"><label>Figure 2.</label><caption><p>Forest plot of insomnia severity index for wearable treatment vs control across 10 randomized controlled trials (adults with insomnia, published between 2017 and 2025). Pooled estimates were calculated using the Hartung&#x2011;Knapp&#x2011;Sidik&#x2011;Jonkman random-effects model, with the Nagashima correction for prediction intervals [<xref ref-type="bibr" rid="ref41">41</xref>-<xref ref-type="bibr" rid="ref43">43</xref>,<xref ref-type="bibr" rid="ref47">47</xref>-<xref ref-type="bibr" rid="ref51">51</xref>,<xref ref-type="bibr" rid="ref54">54</xref>,<xref ref-type="bibr" rid="ref56">56</xref>]. MD: mean difference.</p></caption><graphic alt-version="no" mimetype="image" position="float" xlink:type="simple" xlink:href="jmir_v28i1e93496_fig02.png"/></fig></sec><sec id="s3-5"><title>Objective Sleep Outcomes</title><p>A series of meta-analyses was conducted for objective TST (n=9), SOL (n=5), WASO (n=5), SE (n=7), and the ESS (n=2), as shown in <xref ref-type="fig" rid="figure3">Figure 3</xref>. For TST, the random-effects meta-analysis using the HKSJ correction showed a nonsignificant pooled MD of 17.91 (95% CI &#x2212;4.39 to 40.22; PI &#x2212;26.78 to 62.60) minutes. For SOL, a significant reduction was observed, with a pooled MD of &#x2212;4.52 (95% CI &#x2212;8.38 to &#x2212;0.67; PI &#x2212;9.52 to 0.47) minutes, indicating that wearable interventions shortened the time to fall asleep compared with controls. The meta-analyses found that wearable interventions did not have a statistically significant effect on WASO (MD 2.68, 95% CI &#x2212;4.00 to 9.37, PI &#x2212;6.30 to 11.39 minutes), SE (MD 2.10%, 95% CI &#x2212;3.74% to 7.95%; PI &#x2212;12.47% to 16.67%), and ESS (MD 2.60, 95% CI &#x2212;8.60 to 13.80; PI &#x2212;13.34 to 18.54 points).</p><fig position="float" id="figure3"><label>Figure 3.</label><caption><p>Forest plots of objective sleep outcomes for the wearable intervention vs control. Pooled estimates were calculated using the Hartung&#x2011;Knapp&#x2011;Sidik&#x2011;Jonkman random-effects model, with the Nagashima correction applied to the prediction intervals. (A) Total sleep time (<italic>k</italic>=9): nonsignificant (mean difference [MD] 17.91, 95% CI &#x2212;4.39 to 40.22 min; <italic>I</italic>&#x00B2;=61.3%). (B) Sleep-onset latency (<italic>k</italic>=5): significant reduction (MD &#x2212;4.52, 95% CI &#x2212;8.38 to &#x2212;0.67 min; I&#x00B2;=18.8%). (C) Wake after sleep onset (<italic>k</italic>=5): nonsignificant (MD 2.68, 95% CI &#x2212;4.00 to 9.37 min; <italic>I</italic>&#x00B2;=0%). (D) Sleep efficiency (<italic>k</italic>=7): nonsignificant (MD 2.10%, 95% CI &#x2212;3.74% to 7.95%; <italic>I</italic>&#x00B2;=79.0%). (E) Epworth Sleepiness Scale (<italic>k</italic>=2): nonsignificant (MD 2.60, 95% CI &#x2212;8.60 to 13.80 points; <italic>I</italic>&#x00B2;=0%) [<xref ref-type="bibr" rid="ref43">43</xref>,<xref ref-type="bibr" rid="ref45">45</xref>,<xref ref-type="bibr" rid="ref47">47</xref>-<xref ref-type="bibr" rid="ref52">52</xref>,<xref ref-type="bibr" rid="ref54">54</xref>,<xref ref-type="bibr" rid="ref56">56</xref>].</p></caption><graphic alt-version="no" mimetype="image" position="float" xlink:type="simple" xlink:href="jmir_v28i1e93496_fig03.png"/></fig></sec><sec id="s3-6"><title>Subjective Sleep Outcomes</title><p>Meta-analyses were conducted for subjective sleep outcomes, including TST (n=4), SOL (n=4), WASO (n=3), SE (n=4), ESS (n=3), sleep quality (n=3), and PSQI (n=5), as shown in <xref ref-type="fig" rid="figure4">Figure 4</xref>. Subjective SE showed a small beneficial effect (MD 2.00%, 95% CI 1.90%&#x2010;2.11%; PI 1.85%&#x2010;2.15%) in the wearable group compared with controls. Subjective TST was significantly improved (MD 19.11, 95% CI 2.98&#x2010;35.24; PI &#x2212;16.20 to 54.43 min), suggesting inconsistent efficacy across individual trials despite the statistically significant pooled overall effect. For the remaining subjective sleep end points, all 95% CIs crossed the null value and demonstrated no statistically meaningful intervention benefits: subjective SOL (MD &#x2212;4.0, 95% CI &#x2212;13.15 to 5.14; PI &#x2212;16.46 to 8.46 min), subjective WASO (MD &#x2212;1.86, 95% CI &#x2212;27.88 to 24.15; PI &#x2212;8.95 to 5.31 min), subjective ESS (MD &#x2212;0.22, 95% CI &#x2212;3.37 to 2.93, PI &#x2212;5.70 to 5.26 points), subjective sleep quality (MD 0.01, 95% CI &#x2212;0.38 to 0.40, PI &#x2212;0.45 to 0.47 points), and PSQI (MD &#x2212;1.61, 95% CI &#x2212;3.71 to 0.49; PI &#x2212;6.03 to 2.81 points).</p><fig position="float" id="figure4"><label>Figure 4.</label><caption><p>Forest plots of subjective sleep outcomes for wearable interventions vs control in adults with insomnia (randomized controlled trials, published between 2017 and 2025). Pooled estimates were calculated using the Hartung&#x2011;Knapp&#x2011;Sidik&#x2011;Jonkman random-effects model, with the Nagashima correction applied to prediction intervals (PIs). (A) Total sleep time (<italic>k</italic>=4): significant increase (MD 19.11, 95% CI 2.98 to 35.24 min), but the PI crossed zero (PI &#x2212;16.20 to 54.43), indicating variable effects across trials. (B) Sleep-onset latency (<italic>k</italic>=4): nonsignificant (MD &#x2212;4.0, 95% CI &#x2212;13.15 to 5.14 min). (C) Wake after sleep onset (<italic>k</italic>=3): nonsignificant (MD &#x2212;1.86, 95% CI &#x2212;27.88 to 24.15 min). (D) Sleep efficiency (<italic>k</italic>=4): significant improvement (MD 2.00%, 95% CI 1.90% to 2.11%). (E) Epworth Sleepiness Scale (<italic>k</italic>=3): nonsignificant (MD &#x2212;0.22, 95% CI &#x2212;3.37 to 2.93 points). (F) Sleep quality (<italic>k</italic>=3): nonsignificant (MD 0.01 points, 95% CI &#x2212;0.38 to 0.40 points). (G) Pittsburgh Sleep Quality Index (<italic>k</italic>=5): nonsignificant reduction (MD &#x2212;1.61, 95% CI &#x2212;3.71 to 0.49 points) [<xref ref-type="bibr" rid="ref41">41</xref>-<xref ref-type="bibr" rid="ref43">43</xref>,<xref ref-type="bibr" rid="ref46">46</xref>,<xref ref-type="bibr" rid="ref48">48</xref>,<xref ref-type="bibr" rid="ref50">50</xref>-<xref ref-type="bibr" rid="ref53">53</xref>].</p></caption><graphic alt-version="no" mimetype="image" position="float" xlink:type="simple" xlink:href="jmir_v28i1e93496_fig04.png"/></fig></sec><sec id="s3-7"><title>Investigation of Heterogeneity: Meta-Regression</title><p>Subgroup analyses were predefined for multiple sleep outcomes; however, most end points had fewer than 5 trials, precluding reliable subgroup pooling. Accordingly, mixed-effects meta-regression with Hartung-Knapp adjustment was selected as an alternative method to investigate between-study heterogeneity. To identify potential sources of substantial between-study heterogeneity for the ISI, we performed mixed-effects meta-regression with 3 predefined study-level moderators: control type, intervention duration, and device-wearing position. A multivariate model incorporating all 3 covariates was constructed first, followed by 3 separate univariate meta-regression analyses for individual moderator assessment.</p><p>In the multivariate regression model, the omnibus <italic>F</italic> test for combined moderators was nonsignificant (<italic>F</italic><sub>3,6</sub>=0.26; <italic>P</italic>=.85), and these covariates collectively explained 0.00% of interstudy heterogeneity (<italic>R</italic><sup>&#x00B2;</sup>=0.00%). Marked unexplained residual heterogeneity remained after adjustment (residual <italic>I</italic>&#x00B2;=83.48%; residual heterogeneity <italic>Q</italic>&#x2011;statistic<italic>, Q</italic><sub>E</sub>=29.08; <italic>df</italic>=6 for <italic>Q</italic><sub>E</sub>; <italic>P</italic>&#x003C;.001). None of the 3 moderators yielded statistically significant regression coefficients (control type: <italic>P</italic>=.83; intervention duration: <italic>P</italic>=.58; device&#x2011;wearing position: <italic>P</italic>=.60; <xref ref-type="table" rid="table2">Table 2</xref>). Consistent findings were observed in subsequent univariate analyses: control type (<italic>F</italic><sub>1,8</sub>=0.29; <italic>P</italic>=.61), intervention duration (<italic>F</italic><sub>1,8</sub>=0.60; <italic>P</italic>=.46), and device-wearing position (<italic>F</italic><sub>1,8</sub>=0.10; <italic>P</italic>=.76) failed to alter pooled effect estimates. All univariate models returned <italic>R</italic><sup>&#x00B2;</sup> of 0.00%, with residual <italic>I</italic><sup>&#x00B2;</sup> ranging from 78.60% to 80.96%. Overall, the 3 prespecified clinical factors could not account for the high heterogeneity of pooled ISI results.</p><table-wrap id="t2" position="float"><label>Table 2.</label><caption><p>Meta-regression analysis of potential moderators for the insomnia severity index (ISI).</p></caption><table id="table2" frame="hsides" rules="groups"><thead><tr><td align="left" valign="bottom">Moderator</td><td align="left" valign="bottom">Coefficient</td><td align="left" valign="bottom">Standard error</td><td align="left" valign="bottom"><italic>t</italic> test (<italic>df</italic>)</td><td align="left" valign="bottom"><italic>P</italic> value</td><td align="left" valign="bottom">95% CI</td><td align="left" valign="bottom"><italic>R</italic>&#x00B2; (%)<sup><xref ref-type="table-fn" rid="table2fn1">a</xref></sup></td><td align="left" valign="bottom">Residual <italic>I</italic>&#x00B2; (%)<sup><xref ref-type="table-fn" rid="table2fn2">b</xref></sup></td></tr></thead><tbody><tr><td align="left" valign="top" colspan="8">Multivariate model</td></tr><tr><td align="left" valign="top"><named-content content-type="indent">&#x00A0;&#x00A0;&#x00A0;&#x00A0;</named-content>Control type</td><td align="char" char="." valign="top">0.749</td><td align="char" char="." valign="top">3.28</td><td align="char" char="." valign="top">0.228 (6)</td><td align="char" char="." valign="top">.83</td><td align="char" char="." valign="top">&#x2212;7.276 to 8.773</td><td align="char" char="." valign="top">0</td><td align="char" char="." valign="top">83.48</td></tr><tr><td align="left" valign="top"><named-content content-type="indent">&#x00A0;&#x00A0;&#x00A0;&#x00A0;</named-content>Intervention duration</td><td align="char" char="." valign="top">1.883</td><td align="char" char="." valign="top">3.235</td><td align="char" char="." valign="top">0.582 (6)</td><td align="char" char="." valign="top">.58</td><td align="char" char="." valign="top">&#x2212;6.033 to 9.800</td><td align="char" char="." valign="top">0</td><td align="char" char="." valign="top">83.48</td></tr><tr><td align="left" valign="top"><named-content content-type="indent">&#x00A0;&#x00A0;&#x00A0;&#x00A0;</named-content>Device-wearing position</td><td align="char" char="." valign="top">1.723</td><td align="char" char="." valign="top">3.124</td><td align="char" char="." valign="top">0.552 (6)</td><td align="char" char="." valign="top">.60</td><td align="char" char="." valign="top">&#x2212;5.922 to 9.368</td><td align="char" char="." valign="top">0</td><td align="char" char="." valign="top">83.48</td></tr><tr><td align="left" valign="top" colspan="8">Univariate model</td></tr><tr><td align="left" valign="top"><named-content content-type="indent">&#x00A0;&#x00A0;&#x00A0;&#x00A0;</named-content>Control type</td><td align="char" char="." valign="top">1.281</td><td align="char" char="." valign="top">2.396</td><td align="char" char="." valign="top">0.535 (8)</td><td align="char" char="." valign="top">.61</td><td align="char" char="." valign="top">&#x2212;4.244 to 6.806</td><td align="char" char="." valign="top">0</td><td align="char" char="." valign="top">79.81</td></tr><tr><td align="left" valign="top"><named-content content-type="indent">&#x00A0;&#x00A0;&#x00A0;&#x00A0;</named-content>Intervention duration</td><td align="char" char="." valign="top">1.807</td><td align="char" char="." valign="top">2.329</td><td align="char" char="." valign="top">0.776 (8)</td><td align="char" char="." valign="top">.46</td><td align="char" char="." valign="top">&#x2212;3.564 to 7.177</td><td align="char" char="." valign="top">0</td><td align="char" char="." valign="top">78.6</td></tr><tr><td align="left" valign="top"><named-content content-type="indent">&#x00A0;&#x00A0;&#x00A0;&#x00A0;</named-content>Device-wearing position</td><td align="char" char="." valign="top">0.85</td><td align="char" char="." valign="top">2.674</td><td align="char" char="." valign="top">0.318 (8)</td><td align="char" char="." valign="top">.76</td><td align="char" char="." valign="top">&#x2212;5.316 to 7.016</td><td align="char" char="." valign="top">0</td><td align="char" char="." valign="top">80.96</td></tr></tbody></table><table-wrap-foot><fn id="table2fn1"><p><sup>a</sup><italic>R</italic>&#x00B2;: percentage of between-study heterogeneity explained by moderators.</p></fn><fn id="table2fn2"><p><sup>b</sup><italic>I</italic>&#x00B2;: residual unexplained heterogeneity.</p></fn></table-wrap-foot></table-wrap></sec><sec id="s3-8"><title>RoB in Studies</title><p>The RoB in the included RCTs was independently assessed by 2 reviewers using the Cochrane RoB 2.0 tool. Any disagreements were resolved by consensus or consultation with a third investigator. Overall, 4 studies were classified as having a low RoB, 9 as having an unclear RoB, and 3 as having a high RoB (<xref ref-type="fig" rid="figure5">Figure 5</xref>).</p><fig position="float" id="figure5"><label>Figure 5.</label><caption><p>Risk-of-bias (RoB) summary: assessment of the included randomized controlled trials using the Cochrane RoB 2.0 tool [<xref ref-type="bibr" rid="ref41">41</xref>-<xref ref-type="bibr" rid="ref56">56</xref>].</p></caption><graphic alt-version="no" mimetype="image" position="float" xlink:type="simple" xlink:href="jmir_v28i1e93496_fig05.png"/></fig></sec><sec id="s3-9"><title>Reporting Biases</title><p>For the ISI outcome, which included 10 RCTs, we generated funnel plots and applied the random-effects regression test (the regtest function in the metafor package) to assess small-study effects rather than publication bias. We found borderline nonsignificant funnel asymmetry (<italic>z</italic>=&#x2212;1.85; <italic>P</italic>=.06). No quantitative tests for small-study effects were undertaken for the remaining outcomes, as fewer than 10 studies were available, leading to low statistical power.</p></sec><sec id="s3-10"><title>Sensitivity Analysis</title><p>Leave-one-out sensitivity analysis was performed under the HKSJ random-effects model to verify the robustness of the pooled ISI estimate. Sequential exclusion of each individual study did not substantially alter the direction and magnitude of the pooled effect. Excluding the small-sample trial conducted by Jeon and Choi [<xref ref-type="bibr" rid="ref50">50</xref>] eliminated between-study heterogeneity, yet the overall effect remained consistent, which further confirmed the stability of our primary findings.</p></sec><sec id="s3-11"><title>Certainty of Evidence</title><p>The GRADE rating results (<xref ref-type="table" rid="table3">Table 3</xref>) showed that 2 outcomes were rated as moderate certainty due to imprecision, and 3 outcomes were rated as high certainty. Outcomes with fewer than 3 studies were not graded.</p><table-wrap id="t3" position="float"><label>Table 3.</label><caption><p>GRADE<sup><xref ref-type="table-fn" rid="table3fn1">a</xref></sup> summary-of-findings table for wearable digital therapy in adults with insomnia.</p></caption><table id="table3" frame="hsides" rules="groups"><thead><tr><td align="left" valign="bottom" colspan="7">Certainty assessment</td><td align="left" valign="bottom" colspan="2">Patients, n/N (%)</td><td align="left" valign="bottom">Effect</td><td align="left" valign="bottom" rowspan="2">Certainty</td></tr><tr><td align="left" valign="bottom">Number of studies</td><td align="left" valign="bottom">Study design</td><td align="left" valign="bottom">Risk of bias</td><td align="left" valign="bottom">Inconsistency</td><td align="left" valign="bottom">Indirectness</td><td align="left" valign="bottom">Imprecision</td><td align="left" valign="bottom">Other considerations</td><td align="left" valign="bottom">Wearable device</td><td align="left" valign="bottom">Control</td><td align="left" valign="bottom">Absolute (95% CI)</td></tr></thead><tbody><tr><td align="left" valign="top" colspan="11">Insomnia severity index</td></tr><tr><td align="left" valign="top">10</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn2">b</xref></sup></td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn3">c</xref></sup></td><td align="left" valign="top">None</td><td align="left" valign="top">199/383 (52.0)</td><td align="left" valign="top">184/383 (48.0)</td><td align="left" valign="top">MD<sup><xref ref-type="table-fn" rid="table3fn4">d</xref></sup> &#x2013;1.82 (&#x2013;4.33 to 0.69)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x25EF;&#x25EF; Low<sup><xref ref-type="table-fn" rid="table3fn2">b</xref></sup><sup>,<xref ref-type="table-fn" rid="table3fn3">c</xref></sup></td></tr><tr><td align="left" valign="top" colspan="11">Pittsburgh Sleep Quality Index</td></tr><tr><td align="left" valign="top">5</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn5">e</xref></sup></td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn6">f</xref></sup></td><td align="left" valign="top">None</td><td align="left" valign="top">156/318 (49.1)</td><td align="left" valign="top">162/318 (50.9)</td><td align="left" valign="top">MD &#x2013;1.61 (&#x2013;3.71 to 0.49)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x25EF;&#x25EF; Low<sup><xref ref-type="table-fn" rid="table3fn5">e</xref></sup><sup>,<xref ref-type="table-fn" rid="table3fn6">f</xref></sup></td></tr><tr><td align="left" valign="top" colspan="11">Objective total sleep time</td></tr><tr><td align="left" valign="top">9</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn7">g</xref></sup></td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn8">h</xref></sup></td><td align="left" valign="top">None</td><td align="left" valign="top">198/398 (49.7)</td><td align="left" valign="top">200/398 (50.3)</td><td align="left" valign="top">MD 17.91 (&#x2212;4.39 to 40.22)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x25EF;&#x25EF; Low<sup><xref ref-type="table-fn" rid="table3fn7">g</xref></sup><sup>,<xref ref-type="table-fn" rid="table3fn8">h</xref></sup></td></tr><tr><td align="left" valign="top" colspan="11">Subjective total sleep time</td></tr><tr><td align="left" valign="top">4</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">None</td><td align="left" valign="top">89/182 (48.9)</td><td align="left" valign="top">93/182 (51.1)</td><td align="left" valign="top">MD 19.11 (2.98 to 35.24)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x2A01;&#x2A01; High</td></tr><tr><td align="left" valign="top" colspan="11">Objective sleep efficiency</td></tr><tr><td align="left" valign="top">7</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn9">i</xref></sup></td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn10">j</xref></sup></td><td align="left" valign="top">None</td><td align="left" valign="top">140/290 (48.3)</td><td align="left" valign="top">150/290 (51.7)</td><td align="left" valign="top">MD 2.10 (&#x2212;3.74 to 7.95)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x25EF;&#x25EF; Low<sup><xref ref-type="table-fn" rid="table3fn9">i</xref></sup><sup>,<xref ref-type="table-fn" rid="table3fn10">j</xref></sup></td></tr><tr><td align="left" valign="top" colspan="11">Subjective sleep efficiency</td></tr><tr><td align="left" valign="top">4</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">None</td><td align="left" valign="top">109/220 (49.5)</td><td align="left" valign="top">111/220 (50.5)</td><td align="left" valign="top">MD 2.00 (1.90 to 2.11)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x2A01;&#x2A01; High</td></tr><tr><td align="left" valign="top" colspan="11">Objective sleep-onset latency</td></tr><tr><td align="left" valign="top">5</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">None</td><td align="left" valign="top">80/164 (48.8)</td><td align="left" valign="top">84/264 (31.8)</td><td align="left" valign="top">MD &#x2212;4.52 (&#x2212;8.38 to &#x2212;0.67)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x2A01;&#x2A01; High</td></tr><tr><td align="left" valign="top" colspan="11">Subjective sleep-onset latency</td></tr><tr><td align="left" valign="top">4</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn11">k</xref></sup></td><td align="left" valign="top">None</td><td align="left" valign="top">89/182 (48.9)</td><td align="left" valign="top">93/182 (51.1)</td><td align="left" valign="top">MD &#x2013;4.0 (&#x2212;13.15 to 5.14)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x2A01;&#x25EF; Moderate<sup><xref ref-type="table-fn" rid="table3fn11">k</xref></sup></td></tr><tr><td align="left" valign="top" colspan="11">Objective WASO<sup><xref ref-type="table-fn" rid="table3fn12">l</xref></sup></td></tr><tr><td align="left" valign="top">5</td><td align="left" valign="top">Randomized trials</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Not serious</td><td align="left" valign="top">Serious<sup><xref ref-type="table-fn" rid="table3fn13">m</xref></sup></td><td align="left" valign="top">None</td><td align="left" valign="top">113/231 (48.9)</td><td align="left" valign="top">118/231 (51.1)</td><td align="left" valign="top">MD 2.68 (&#x2212;4.00 to 9.37)</td><td align="left" valign="top">&#x2A01;&#x2A01;&#x2A01;&#x25EF; Moderate<sup><xref ref-type="table-fn" rid="table3fn13">m</xref></sup></td></tr></tbody></table><table-wrap-foot><fn id="table3fn1"><p><sup>a</sup>GRADE: Grading of Recommendations, Assessment, Development, and Evaluation.</p></fn><fn id="table3fn2"><p><sup>b</sup>Downgraded one level for substantial heterogeneity (<italic>I</italic>&#x00B2;=73.2%, <italic>P</italic>&#x003C;.001).</p></fn><fn id="table3fn3"><p><sup>c</sup>Downgraded one level for wide CI crossing the null (95% CI &#x2212;4.33 to 0.69) and broad prediction interval.</p></fn><fn id="table3fn4"><p><sup>d</sup>MD: mean difference.</p></fn><fn id="table3fn5"><p><sup>e</sup>Downgraded one level for moderate-to-substantial heterogeneity (<italic>I</italic>&#x00B2;=58.3%; <italic>P</italic>=.026).</p></fn><fn id="table3fn6"><p><sup>f</sup>Downgraded one level for CI crossing the null (95% CI &#x2212;2.73 to 0.45) and broad prediction interval.</p></fn><fn id="table3fn7"><p><sup>g</sup>Downgraded one level for moderate heterogeneity (<italic>I</italic>&#x00B2;=61.3%; <italic>P</italic>=.008).</p></fn><fn id="table3fn8"><p><sup>h</sup>Downgraded one level for CI crossing the null (95% CI &#x2212;4.39 to 40.22) and very broad prediction interval (&#x2212;26.78 to 62.60).</p></fn><fn id="table3fn9"><p><sup>i</sup>Downgraded one level for substantial heterogeneity (<italic>I</italic>&#x00B2;=79.0%; <italic>P</italic>&#x003C;.0001), largely driven by a single outlier (Jeon and Choi [<xref ref-type="bibr" rid="ref50">50</xref>]) with an opposite effect direction; sensitivity analysis excluding this study reduced heterogeneity to 39.9% but the pooled estimate remained nonsignificant.</p></fn><fn id="table3fn10"><p><sup>j</sup>Downgraded one level for wide CI crossing the null (95% CI &#x2212;3.74 to 7.95) and very broad prediction interval (&#x2212;12.47 to 16.67), indicating substantial uncertainty in the true-effect estimate.</p></fn><fn id="table3fn11"><p><sup>k</sup>Downgraded one level for serious imprecision. The wide 95% CI (&#x2212;13.15 to 5.14) crosses the null, including both beneficial and harmful effects, so a clinically meaningful intervention effect cannot be confirmed.</p></fn><fn id="table3fn12"><p><sup>l</sup>WASO: wake after sleep onset.</p></fn><fn id="table3fn13"><p><sup>m</sup>Downgraded one level for CI crossing the null (&#x2212;4.00 to 9.37) and being relatively wide, indicating that the true effect could range from a modest reduction to a clinically meaningful increase in WASO.</p></fn></table-wrap-foot></table-wrap></sec></sec><sec id="s4" sec-type="discussion"><title>Discussion</title><p>This systematic review and meta-analysis of 16 RCTs encompassing 910 participants indicates that stand-alone wearable digital interventions are associated with small yet statistically significant improvements in objective SOL, subjective SE, and subjective TST among adults with insomnia. Nevertheless, these interventions demonstrate no significant benefit for global insomnia severity as measured by the ISI. Through the application of the HKSJ framework with Nagashima-corrected PIs, this study provides more robust effect estimates than prior reviews. Although pooled estimates favor wearable interventions for these specific parameters, the wide 95% PIs suggest that the effect in any given future clinical setting could range from meaningful benefit to negligible or no effect. This implies that while wearable interventions are validated at the population level for certain sleep outcomes, their real-world effectiveness is highly dependent on context [<xref ref-type="bibr" rid="ref57">57</xref>-<xref ref-type="bibr" rid="ref59">59</xref>]. This finding underscores the importance of exploring sources of heterogeneity, a prespecified objective of this review. The certainty of the evidence was rated as moderate to low using GRADE [<xref ref-type="bibr" rid="ref39">39</xref>], reflecting consistent effect direction for specific outcomes while also acknowledging recognized methodological limitations, particularly the inability to blind participants and outcome assessors in wearable device trials.</p><p>The selective efficacy pattern observed in this review suggests that wearable devices target specific physiological and perceptual sleep domains rather than the multifaceted cognitive and behavioral pathology that underlies insomnia disorder [<xref ref-type="bibr" rid="ref60">60</xref>,<xref ref-type="bibr" rid="ref61">61</xref>]. This interpretation aligns with the theoretical understanding that insomnia is not merely a disorder of sleep physiology but also involves maladaptive cognitions, conditioned arousal [<xref ref-type="bibr" rid="ref62">62</xref>], and behavioral factors [<xref ref-type="bibr" rid="ref63">63</xref>] that require targeted psychotherapeutic intervention [<xref ref-type="bibr" rid="ref2">2</xref>]. Hardware-based biofeedback and neuromodulation delivered via wearable devices may facilitate physiological de-arousal and shorten sleep onset [<xref ref-type="bibr" rid="ref54">54</xref>,<xref ref-type="bibr" rid="ref64">64</xref>,<xref ref-type="bibr" rid="ref65">65</xref>]; however, they do not directly address the perpetuating mechanisms of insomnia, such as sleep-related worry, conditioned bed arousal, and irregular sleep schedules, that CBT-I is designed to modify [<xref ref-type="bibr" rid="ref2">2</xref>,<xref ref-type="bibr" rid="ref60">60</xref>,<xref ref-type="bibr" rid="ref66">66</xref>]. The certainty of these findings, however, must be tempered by the underlying evidence quality: objective SOL and subjective SE were rated as high certainty by GRADE, providing confidence that wearable devices produce measurable improvements in these specific parameters. By contrast, subjective TST, though statistically significant, was based on only 4 trials and exhibited a wide PI. Its GRADE rating was high primarily due to consistency across the limited number of studies, a finding that should be interpreted with caution given the small evidence base. Furthermore, the overall RoB assessment (<xref ref-type="fig" rid="figure5">Figure 5</xref>) showed that most included trials had unclear or high RoB across multiple domains. Insufficient blinding of participants and personnel, an inherent challenge in wearable device trials, was the most common concern [<xref ref-type="bibr" rid="ref67">67</xref>] and may have inflated effect estimates for subjective outcomes that rely on self-report. Empirical evidence from meta-epidemiological studies shows that nonblinded assessors exaggerate effect estimates for subjective outcomes by 29% (95% CI, 8&#x2011;45) on average [<xref ref-type="bibr" rid="ref67">67</xref>], and a systematic review reported a 68% exaggeration [<xref ref-type="bibr" rid="ref68">68</xref>]. These findings suggest that the true effects of wearable interventions on subjective sleep outcomes may be smaller than observed. Additionally, several studies had high or unclear RoB due to incomplete outcome data, such as attrition rates exceeding 20% in some trials, a lack of intention-to-treat analysis, or inadequate reporting of randomization and allocation concealment. These methodological limitations, especially when combined with small sample sizes and variable adherence, suggest that the observed effects may be overestimated. Consequently, our more modest and selective findings, compared with larger effect sizes reported for comprehensive digital CBT-I, likely reflect the genuine stand-alone contribution of wearable hardware rather than the confounded psychotherapeutic effects present in prior pooled analyses.</p><p>The subjective-objective discrepancy identified in our analysis is consistent with the well-documented phenomenon of sleep misperception in insomnia. Patients with insomnia often underestimate their sleep duration and overestimate their wakefulness relative to objective recordings, a pattern known as paradoxical insomnia or sleep-state misperception [<xref ref-type="bibr" rid="ref69">69</xref>,<xref ref-type="bibr" rid="ref70">70</xref>]. Our finding that objective SOL shortened, whereas subjective TST exhibited considerable between-study variability implies that wearable devices may induce genuine physiological changes in sleep onset without necessarily correcting the perceptual distortions that characterize insomnia [<xref ref-type="bibr" rid="ref61">61</xref>]. This observation has direct implications for patient counseling: individuals using wearable devices may experience faster objective sleep onset but may not perceive a corresponding improvement in overall sleep quality or duration, which could lead to continued dissatisfaction. Ahn et al [<xref ref-type="bibr" rid="ref71">71</xref>] further showed that greater sleep-wake state discrepancy was associated with poorer treatment response, indicating that unresolved perceptual distortions may undermine perceived treatment benefit even when objective sleep metrics improve.</p><p>In comparison with existing syntheses, the modest therapeutic impact of stand-alone wearables becomes apparent. Unlike digital CBT-I programs evaluated in previous reviews [<xref ref-type="bibr" rid="ref29">29</xref>,<xref ref-type="bibr" rid="ref30">30</xref>], which address both sleep physiology and the cognitive behavioral perpetuating factors of insomnia, our exclusive focus on wearable hardware reveals improvements limited to specific sleep parameters rather than global insomnia resolution. Reviews of consumer sleep technology [<xref ref-type="bibr" rid="ref31">31</xref>,<xref ref-type="bibr" rid="ref32">32</xref>] have largely focused on measurement rather than therapeutic efficacy and did not quantitatively compare different device types or intervention durations. Lai et al [<xref ref-type="bibr" rid="ref33">33</xref>] previously conducted a review that specifically examined wearable-delivered interventions but pooled heterogeneous populations and did not target insomnia disorder exclusively. Our findings advance this prior work by demonstrating that, in a homogeneous insomnia population, wearables produce selective benefits that are significant for sleep onset and perceived efficiency but not for global insomnia severity, thereby clarifying their appropriate role as adjunctive rather than primary interventions.</p><p>From a methodological perspective, the application of Nagashima-corrected PIs [<xref ref-type="bibr" rid="ref34">34</xref>] offers a more nuanced interpretation than conventional confidence intervals alone. For example, although objective SOL demonstrated a statistically significant average effect, the PI suggested that the true effect in future individual settings could range from meaningful benefit to negligible change or even no effect. Similarly, the significant average improvement in subjective TST was accompanied by a PI that crossed zero, implying that the perceived benefit is inconsistent across settings and may depend on unmeasured moderators, such as baseline sleep misperception severity, device engagement, or placebo expectations. This distinction between average effects and effect distributions is of paramount importance for clinical decision-making: a statistically significant confidence interval confirms that an intervention works on average across trials, whereas the PI reveals whether it is likely to work in a particular clinical setting or for a given individual patient [<xref ref-type="bibr" rid="ref58">58</xref>].</p><p>The high unexplained heterogeneity for ISI (residual <italic>I</italic>&#x00B2;=83.48% after meta-regression) is noteworthy. The inability of control type, intervention duration, and device-wearing position to explain this heterogeneity implies that the true variability in treatment effects may be attributable to factors that were not captured in published aggregate data. One such factor may be baseline objective sleep duration. Bathgate et al [<xref ref-type="bibr" rid="ref72">72</xref>] showed that patients with insomnia with objectively measured short sleep duration (&#x003C;6 h) exhibited a significantly blunted response to CBT-I compared with those with normal sleep duration (&#x2265;6 h), suggesting that patients with a more biologically severe insomnia phenotype may be less responsive to behavioral interventions in general. If baseline objective sleep duration similarly moderates response to wearable devices, its absence from the included trials may account for at least part of the unexplained heterogeneity we observed. Other potential sources include baseline insomnia severity, comorbid mental health conditions, concomitant sleep medication use, and individual differences in sleep physiology and perception. Head-worn devices typically use EEG, which provides a direct and physiologically precise measure of sleep and may enable more targeted neuromodulation [<xref ref-type="bibr" rid="ref73">73</xref>,<xref ref-type="bibr" rid="ref74">74</xref>]. In contrast, wrist-worn actigraphy, while convenient, is prone to overestimating sleep by misclassifying quiet wakefulness as sleep [<xref ref-type="bibr" rid="ref75">75</xref>]. Furthermore, inconsistent operational standards for wearable device calibration across different manufacturers could also contribute to measurement variation [<xref ref-type="bibr" rid="ref27">27</xref>,<xref ref-type="bibr" rid="ref76">76</xref>]. Of note, although device-wearing position differed across included trials, our prespecified meta-regression confirmed that such hardware divergence was not a statistically significant source of heterogeneity for ISI.</p><p>The RoB and GRADE assessments provide important context for our findings. Of the 16 included trials, 9 had an unclear overall RoB and 3 had a high risk, largely attributable to the inherent difficulty of blinding participants and personnel in wearable device trials [<xref ref-type="bibr" rid="ref39">39</xref>]; consequently, the pooled estimates may be subject to performance and detection bias. The direction of such bias likely favors the intervention group, meaning that the true effects may be smaller than observed. According to the GRADE assessment, 3 outcomes were rated as high certainty, 2 as moderate certainty, and 4 as low certainty (<xref ref-type="table" rid="table3">Table 3</xref>). The high-certainty outcomes provide confidence that wearable devices produce measurable improvements in these specific parameters. By contrast, the moderate- and low-certainty ratings for the remaining outcomes, resulting from imprecision, inconsistency, or both, indicate that the true effects may differ materially from the pooled estimates, and clinical recommendations derived from these outcomes should be viewed as conditional rather than definitive.</p><p>Several limitations should be considered when interpreting the findings of this review. First, the modest number of studies contributing to several pooled outcomes (fewer than 5 trials for roughly half of the analyses) constitutes an important limitation that restricts the statistical reliability of the corresponding estimates and precludes meaningful meta-regression for these end points. The inability to obtain individual patient data further prevented the exploration of patient-level predictors of treatment response, which likely represent key sources of the unexplained heterogeneity we observed for ISI [<xref ref-type="bibr" rid="ref57">57</xref>]. Future studies with larger numbers of trials and standardized reporting of individual-level characteristics are needed to confirm the robustness of these findings. Second, the predominance of unclear or high RoB across most included trials, primarily due to insufficient blinding as an inherent challenge in wearable device trials, may have inflated effect estimates for subjective outcomes that rely on self-report. Moreover, most trials had intervention durations of 3 months or less, so the long-term efficacy and sustainability of wearable interventions beyond this timeframe remain unknown [<xref ref-type="bibr" rid="ref77">77</xref>]. Future trials should incorporate longer follow-up periods and more rigorous blinding procedures where feasible. Third, most participants were of East Asian or North American origin, with limited representation from other regions; females predominated, and mean ages varied substantially. Therefore, the findings may not be generalizable to male-only populations, younger adults, or non-Asian and non-Western populations. Future research should prioritize diverse and representative samples to enhance generalizability.</p><p>These findings have several practical clinical implications. Consistent with the objective-subjective outcome discrepancy we identified, wearable devices should be considered an adjunct rather than a substitute for first-line CBT-I. This view is supported by Spina et al [<xref ref-type="bibr" rid="ref61">61</xref>], who found that providing feedback on wearable-measured sleep data reduced insomnia severity (<italic>d</italic>=0.51), although this effect was modest compared with established CBT-I effect sizes (<italic>d</italic>=0.85). These devices provide objective sleep biofeedback and facilitate continuous monitoring. Head-mounted EEG equipment enables precise physiological measurement, whereas wrist-worn trackers may overestimate sleep duration [<xref ref-type="bibr" rid="ref27">27</xref>,<xref ref-type="bibr" rid="ref76">76</xref>]; therefore, head-worn devices may be better suited for improving objective sleep parameters, although cost and tolerability must be carefully considered in clinical practice. The selective efficacy pattern suggests that wearables may be most appropriate for patients with predominant sleep-onset difficulties or those who perceive their sleep as inefficient. Clinicians should consider baseline patient characteristics, including insomnia subtype, comorbidity, and treatment expectations, when recommending wearables, and they should manage expectations concerning the likely magnitude and consistency of benefit. For future research, large and long-term RCTs are needed to establish long-term efficacy. Novel trials should collect detailed participant baseline data to address unexplained heterogeneity and should include daytime function and quality-of-life outcomes. The integration of wearable real-time feedback with digital CBT-I represents a promising avenue for individualized insomnia management.</p><p>This meta-analysis has several strengths. It strictly followed Cochrane systematic review guidance, and the literature search was updated as of May 2026 with 2 newly added RCTs. Stratified analyses that separated objective and subjective sleep indicators helped clarify the distinct discrepancy in efficacy between physiological recordings and patient-reported outcomes. Meta-regression was used instead of fragmented subgroup analyses to systematically explore prespecified confounding moderators contributing to ISI heterogeneity, consistent with current methodological standards. Comprehensive methodological assessments, including RoB evaluation, small-study effect detection via Egger test, leave-one-out sensitivity analysis, and GRADE certainty ratings, further strengthened the reliability and transparency of the results.</p><p>In conclusion, the evidence from this review positions stand-alone wearable devices as a potentially valuable but limited tool in the insomnia therapeutic landscape. Their greatest promise likely lies not in replacing first-line therapies but in serving as an objective feedback mechanism and monitoring adjunct that could enhance patient engagement and enable treatment personalization. To move beyond the current paradigm of population-level efficacy but context-dependent effectiveness, the field must pivot from simple efficacy trials toward implementation science. Future research should prioritize the development and evaluation of hybrid models that combine wearable biofeedback with digital CBT-I, invest in large-scale, long-term pragmatic trials across diverse populations, and leverage individual patient data to clarify the heterogeneity of response. By doing so, it becomes possible to unlock the full potential of wearable therapeutics, shifting from a one-size-fits-all approach toward a stratified insomnia management pathway that aligns technological capabilities with patients&#x2019; specific pathophysiological and psychological profiles.</p></sec></body><back><ack><p>No generative AI or AI-assisted technologies were used in the writing, analysis, or preparation of this manuscript.</p></ack><notes><sec><title>Funding</title><p>This work was supported by the Guangdong Nursing Association General Project (Grant: GDSHLXHYJYB202605) and the Key Project of the First Clinical Medical College of Jinan University (Grant: 802318). The funders had no role in study design, data collection, analysis, interpretation, or manuscript writing.</p></sec><sec><title>Data Availability</title><p>The data that support the findings of this study are available from the corresponding author upon reasonable request.</p></sec></notes><fn-group><fn fn-type="con"><p>Conceptualization: WZ</p><p>Data curation: WZ, MC</p><p>Formal analysis: WZ</p><p>Investigation: WZ, MC, YG</p><p>Methodology: WZ</p><p>Project administration: WZ</p><p>Supervision: BZ, CL (equal)</p><p>Visualization: WZ</p><p>Writing &#x2013; original draft: WZ</p><p>Writing &#x2013; review &#x0026; editing: WZ, MC, YG, BZ, CL</p><p>BZ and CL served as co-corresponding authors.</p></fn><fn fn-type="conflict"><p>None declared.</p></fn></fn-group><glossary><title>Abbreviations</title><def-list><def-item><term id="abb1">EEG</term><def><p>electroencephalography</p></def></def-item><def-item><term id="abb2">ESS</term><def><p>Epworth Sleepiness Scale</p></def></def-item><def-item><term id="abb3">GRADE</term><def><p>Grading of Recommendations, Assessment, Development, and Evaluation</p></def></def-item><def-item><term id="abb4">ISI</term><def><p>insomnia severity index</p></def></def-item><def-item><term id="abb5">MD</term><def><p>mean difference</p></def></def-item><def-item><term id="abb6">PI</term><def><p>prediction interval</p></def></def-item><def-item><term id="abb7">PRISMA</term><def><p>Preferred Reporting Items for Systematic Reviews and Meta&#x2011;Analyses</p></def></def-item><def-item><term id="abb8">PRISMA-S</term><def><p>Preferred Reporting Items for Systematic Reviews and Meta&#x2011;Analyses Literature Search Extension</p></def></def-item><def-item><term id="abb9">PROSPERO</term><def><p>International Prospective Register of Systematic Reviews</p></def></def-item><def-item><term id="abb10">PSQI</term><def><p>Pittsburgh Sleep Quality Index</p></def></def-item><def-item><term id="abb11">RCT</term><def><p>randomized 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