Neuropsychological Assessments of Cognitive Impairment in Major Depressive Disorder: A Systematic Review and Meta-Analysis with Meta-Regression Open Access

Major depressive disorder (MDD) is one of the most common and disabling psychiatric disorders, affecting about 280 million individuals (or 5% of the adult population) globally [1, 2]. Cognitive dysfunction or deficits are well established in patients with MDD [3‒6]. For example, about two-thirds of patients with MDD reported cognitive impairment [7], and two meta-analytic studies [8, 9] reported that patients with MDD, when compared to healthy controls, had small to moderate effect sizes of cognitive deficits. Furthermore, such cognitive deficits in MDD play a principal mediating role of psychosocial impairment, including workforce performance [3, 4, 10], and may elevate the risk of developing other chronic conditions, such as Alzheimer’s disease and related dementias (ADRD) [11, 12].

To date, four meta-analytic studies [8, 9, 13, 14] have compared the cognitive deficits (or impairment) between currently depressed patients with a clinical diagnosis of MDD and healthy subjects. One study [8] published in 2009 examined (1) episodic memory (e.g., immediate and delayed recall, learning and recognition), (2) executive function (e.g., working memory, selective attention, cognitive flexibility, set shifting, planning/problem solving), (3) processing speed, (4) semantic memory, and (5) visuospatial memory using multiple types of neuropsychological tests. This study included 14 studies for its final systematic review and meta-analysis and concluded that patients with MDD had significant cognitive deficits in episodic memory, executive function, and processing speed, but not for sematic or visuospatial memory. Another study conducted in 2013 [9] included 24 studies and found moderate cognitive deficits in executive function, memory, and attention among patients with MDD when compared to healthy controls. Other older studies [13, 14] produced similar findings.

There are several limitations in previous studies, which our study aims to address. First, as stated in the previous study [9], one of methodological drawbacks is related to use of different, multiple neuropsychological tests that were used across the studies and lack of implementation of standardized effect sizes to reflect the magnitude of cognitive impairment [8, 13, 14]. Furthermore, earlier studies may not reflect the results as more contemporary studies have improved methodological approaches. Second, earlier studies did not distinguish effect sizes of cognitive impairment by medication status [8, 14], treatment-resistant status (e.g., those who are eligible for electroconvulsive therapy) [8, 9, 13, 14], or among children or older adult populations [8, 9, 13]. Third, these studies [8, 9, 13, 14] did not assess (1) potential moderators (e.g., age, sex, sample sizes, and geographic regions) using meta-regression analyses and/or (2) quality assessment of individual studies, including publication bias. Our study aimed to explicitly address these gaps.

While there are multiple neuropsychological tests to assess cognitive impairment in MDD, there is no gold standard [3]. Consistent with an earlier study [9], we focused on studies that employed the Cambridge Neuropsychological Test Automated Battery (CANTAB) [15] that was originally developed to assess multiple domains of cognitive function in the 1980s. It provides objective, culturally sensitive, and validated measures of cognitive function that are highly correlated to neural networks [15]. Multidimensional domains of cognitive function (e.g., executive function, memory, attention, and reaction) using multiple measures are described in Table 1. Furthermore, CANTAB is a widely used neuropsychological assessment across diverse clinical conditions (e.g., mood disorders, traumatic brain injury, and ADRD) and study settings globally, resulting in over 3,000 peer-reviewed publications. In the era of digital health and telehealth, CANTAB is also widely known for its accessibility and validity of digital cognitive assessments [15].

The objective of this study was to conduct and update a systematic review and meta-analysis with meta-regression to synthesize the evidence of cognitive impairment in patients with MDD relative to healthy controls, using a single neuropsychological test battery, CANTAB. Our rationale for using CANTAB measures alone was to enable assessment of a wide range of cognitive domains while maintaining inter-study homogeneity of measurements. Consistent with earlier studies [8, 9], we hypothesized that cognitive deficits would be found in patients with MDD when compared to healthy subjects.

The protocol pertaining to this study was registered on PROSPERO (CRD42023433574). A systematic search was conducted from inception to May 23, 2023. The following databases were systematically searched: PubMed/MEDLINE, PsycINFO, Web of Science, the Cochrane Library, and Embase using Medical Subject Headings (MeSH) terms and text keywords. We also manually searched all relevant studies on Google Scholar (https://scholar.google.com/). No language restrictions were imposed. Search strategies are provided in eTable 1 (for all online suppl. material, see https://doi.org/10.1159/000535665) in the Supplement, which also covers the search terms used in the previous study [9]. This study followed the preferred reporting items for meta-analysis of observational studies in epidemiology (MOOSE) reporting guidelines [24] (online suppl. eTable 2). Our study used publicly available data and did not include human participant research. As per 45 CFR §46.102(f), this study was not submitted for institutional review board approval and did not require informed consent procedures.

Inclusion criteria were established prior to article reviews and were as follows: (1) patients with a diagnosis of MDD using standardized diagnostic criteria (e.g., Diagnostic and Statistical Manual of Mental Disorders, Fifth Edition [DSM-5] or International Statistical Classification of Diseases and Related Health Problems, Tenth Revision [ICD-10]); (2) healthy controls (i.e., those [a] without MDD or other psychiatric conditions and [b] are similar to patients with MDD otherwise in terms of patient characteristics); (3) neuropsychological assessments of cognitive impairment using CANTAB (Table 1) in both patients with MDD and healthy controls; and (4) reports of sufficient data (e.g., mean differences and standard deviations) to quantify standardized effect sizes. For patients with MDD, severity of depressive symptoms using validated measures (e.g., Montgomery-Asberg Depression Rating Scale [MADRS] and Hamilton Depression Rating Scale [HDRS or HAMD]) should also have been reported. Exclusion criteria were (1) nonhuman studies and (2) no use of validated measures for MDD or outcomes of interest. We only considered currently depressed patients and not remitted depressed patients because a study focusing on the latter group has been recently reported [25].

Titles and abstracts were independently screened by two reviewers (T.G.R. and S.R.S.), and articles identified as potentially relevant by at least one reviewer were retrieved and duplicates were removed. Full-text articles were independently screened by the same reviewers, and discrepancies were resolved through discussion. Data from included articles were independently extracted by the two reviewers using a pilot-tested data extraction form and then corroborated, with discrepancies resolved through discussion. Information to be extracted was established a priori and included: study characteristics (e.g., PICOTS framework), participant characteristics and subgroups, sample source and collection period, modes of ascertainment, methods of data analysis, selection of cases and controls, and quantitative data pertaining to any primary and secondary outcomes along with covariates. For longitudinal or interventional studies, only baseline data were used. To ensure the absence of overlapping data and to maintain the meta-integrity, data and references for each included study were carefully cross-checked.

The risk of bias and methodological quality were evaluated using the Newcastle-Ottawa scale for the assessment of the quality of non-randomized studies in meta-analyses [26]. We assessed eight items across three domains: selection (adequate definition of case; representativeness of case; definition of control; selection of control); comparability of cases and controls based on the design or analysis; and exposure/outcome (ascertainment of exposure or outcome; same method of ascertainment for cases and controls; and nonresponse rate). The overall quality was classified as being indicative of a “good quality,” “fair quality,” or “poor quality” [26].

Publication bias is always a concern for evidence synthesis. We used funnel plots to visually explore for evidence of association between the effect sizes and statistical precision [27]. We supplemented visual assessments with statistical testing of funnel plot asymmetry using Egger’s test (i.e., a weighted linear regression of effect size vs. precision) and Begg and Mazumdar’s test (i.e., rank correlation test). Evidence of associations between effect sizes and precision across studies may indicate design heterogeneity, chance, or selection biases that operate cross the evidence base (e.g., publication and outcome reporting bias).

We used a Hedges’ g standardized mean difference (SMD) for differences in severity of cognitive impairment between patients with MDD and healthy controls. The weight of each study was determined using an inverse-variance method [27], with a restricted maximum likelihood estimator technique [28]. We used both Cochran’s Q-statistic and I² statistic to quantify the proportions of heterogeneity due to within- and between-study variations [27]. To adequately estimate the overall effect sizes, SMDs with their corresponding 95% confidence intervals (CIs) were calculated using a fixed- or random-effects models, depending on the model assumptions [27]. More specifically, a random-effects model was used when I² statistic was >50%, and a fixed-effects model was used when I² statistic was <50%. We reported both random- and fixed-effects models when I² statistics was 50%. When describing heterogeneity using the I² statistic, we followed the guidance from the Cochrane handbook (i.e., 0–40% as minimal; 30–60% as moderate; 50–90% as substantial; and 75–100% as considerable heterogeneity) [27].

When some studies reported multiple effect sizes for a single domain (e.g., reporting effect sizes of two or more measures for executive function), we used a two-stage meta-analysis. In the first stage, we obtained the overall effect size estimate of multiple measures within the study using a three-level meta-analysis [29]. In the second stage, we pooled and obtained the overall effect size estimate using one effect size from each study. This approach avoids potential duplicates of the samples included. In addition, we performed four subgroup analyses: (1) unmedicated MDD versus healthy controls; (2) treatment-resistant depression (TRD) (defined by individual studies) versus healthy controls; (3) MDD versus healthy controls among children aged ≤18; and (4) MDD versus healthy controls among older adults ≥50.

We also conducted moderator analyses using meta-regression analyses in each of 10 outcome measures by study sample size; age; female sex (%); children, older adults; medication status; TRD status; and region. Medication status (yes or no) refers to any antidepressants (with or without other psychotropic medications) prescribed for managing MDD. TRD was defined as a failure to respond to two or more trials of antidepressant therapies. In particular, those with electroconvulsive therapy referral [30] or deep brain stimulation recipients [31, 32] were considered to have TRD. When identifying potential moderators, we used the variance of the true effects using a restricted maximum likelihood estimator [27]. We used a statistical software, R 4.2.1. (R Foundation for Statistical Computing) for all analyses using the “meta,” “rmeta,” and “metafor” packages [33]. A two-sided p value <0.05 was considered for statistical significance. Finally, as mentioned earlier, we assessed publication bias (or small-study effects) using funnel plots [27]. Egger’s test and Begg and Mazumdar’s test were also performed when assessing the publication bias [27]. Unless otherwise noted, a two-sided p value <0.05 was considered statistically significant.

The literature search yielded 982 articles, of which 42 were eligible after screening titles and abstracts and removing duplicates. Of these eligible studies, 15 were further excluded after full-text screening. Two independent investigators (T.G.R. and S.R.S.) discovered 8 additional studies by manually searching reference lists and Google Scholar (Fig. 1). Overall, 33 studies [30‒32, 34‒63] consisting of 2,596 subjects (n = 1,337 for patients with MDD and n = 1,259 for healthy controls) were included in the review (Table 2). All studies were conducted in hospital settings, except one study [49] that did not specify the study setting. Four studies [34, 40, 43] focused on older adult populations; two studies [55, 60] focused on child populations; and three studies [30‒32] focused on patients with TRD. Of 33 studies, 10 (30.3%) were conducted in the UK, 7 (23.3%) were conducted in the USA, and 16 (48.5%) were conducted in other regions. Sample sizes ranged from 30 to 265. Table 2 provides details of characteristics, including severity of depressive symptoms in patients with MDD, for all included studies.

Overall, patients with MDD, when compared to healthy controls, had significant moderate cognitive deficits (SMD, −0.39 [95% CI, −0.47 to −0.31]; Cochran’s Q-statistic, p = 0.19) with minimal heterogeneity due to within- and between-study variations (I² statistic = 27%) (Fig. 2). While there was no significant difference in reaction time between patients with MDD and healthy controls (SMD, −0.15 [95% CI, −0.53 to 0.24]), patients with MDD had significant moderate cognitive deficits in executive function (SMD, −0.35 [95% CI, −0.47 to −0.23]), memory (SMD, −0.43 [95% CI, −0.55 to −0.31]), and attention (SMD, −0.49 [95% CI, −0.78 to −0.20]) (Fig. 2). Neuropsychological assessments by individual outcome measures were also reported (online suppl. eFig. 1).

We further performed four subgroup analyses (Fig. 3). First, we compared patients with MDD who were not prescribed medications (e.g., antidepressants) versus healthy controls (Fig. 3a). Patients with unmedicated MDD had relatively small but significant cognitive deficits when compared to healthy controls (SMD, −0.19 [95% CI, −0.37 to −0.00]; Cochran’s Q-statistic, p < 0.01). Heterogeneity due to within- and between-study variations was substantial, however (I² statistic = 61%). Memory was the only domain that had a significant difference between the two groups (SMD, −0.26 [95% CI, −0.43 to −0.09]).

Second, we compared patients with TRD versus healthy controls (Fig. 3b), and the effect size was moderate (SMD, −0.56 [95% CI, −0.78 to −0.34]; Cochran’s Q-statistic, p = 0.23), indicating that patients with TRD had moderate cognitive deficits. The heterogeneity due to within- and between-study variations was minimal in this case (I² statistic = 27%). Patients with TRD had significant cognitive deficits in terms of executive function, memory, and attention, but not in reaction time.

Third, we compared patients with MDD versus healthy controls among children (Fig. 3c). We did not find any statistically significant difference in cognitive impairment among children. Last, we compared patients with MDD versus health controls among older adults (Fig. 3d). Among older adults, patients with MDD had moderate cognitive deficits when compared to healthy controls (SMD, −0.51 [95% CI, −0.66 to −0.36]; Cochran’s Q-statistic, p = 0.38). Heterogeneity due to within- and between-study variations was minimal in this case (I² statistic = 7%). In particular, patients with MDD had significant moderate cognitive deficits in memory (SMD, −0.48 [95% CI, −0.66 to −0.30]) and attention (SMD, −0.82 [95% CI, −1.20 to −0.44]).

We have also fully explored potential moderating roles of the following variables in each of 10 outcome measures using meta-regression models: study sample size; age; female sex (%); children; older adults; medication status; TRD status; and region by individual outcome measures (online suppl. eTable 3). The study sample size was a potential moderator for delayed matching to sample (p < 0.001) and paired associates learning (p = 0.02). Age was a potential moderator for spatial recognition memory (p = 0.04). Being a child was a potential moderator for (one touch) stockings of Cambridge (OTS/SOC) (p = 0.03). Medication status was a potential moderator for intra-extra dimensional set shift (p = 0.003) and rapid visual information processing (RVP) (p = 0.01). Finally, geographic region was a potential moderator for pattern recognition memory (p = 0.006).

Methodological quality of the included studies was considered “good,” and we provided our justification on online suppl. eTable 4 in the supplement. In our main analysis, we did not find any potential publication bias (online suppl. eFig. 2) using the Egger’s test (p = 0.74) and Begg and Mazumdar’s test (p = 0.93). In our subgroup analyses, we did not find any evidence for publication bias (online suppl. eFig. 3). We also reported the tests of publication bias by individual outcome measures (online suppl. eFig. 4), in which we did not find any evidence for publication bias.

The current study updates previous systematic review and meta-analytic works [8, 9]. Our findings are consistent with these earlier studies [8, 9], indicating that those who are currently depressed, when compared to healthy subjects, had significant moderate cognitive deficits across the domains of executive function, memory, and attention, but not in the reaction time domain. Furthermore, our study extends findings of previous studies [8, 9] by conducting subgroup analyses by medication status, treatment-resistant status, and among children and older adult populations. In our subgroup analyses, currently depressed patients who are unmedicated had a small effect size of cognitive deficits, and no significant effect sizes were found among children, but those with treatment resistance and among older adults had moderate to large effect sizes of cognitive deficits across multiple cognitive domains. In summary, our systematic review and meta-analysis demonstrate that moderate cognitive deficits are found in currently depressed patients when compared to healthy controls.

Our study only included studies that had used CANTAB tasks to assess cognitive function in currently depressed patients relative to healthy controls. While the magnitudes of cognitive deficits recorded in our findings are broadly in line with previous studies, our non-significant finding of cognitive deficit in reaction time in MDD when compared to healthy controls contrasted with the literature [9]. This may be due in part to variability of patient characteristics and/or study designs and settings. Meta-analytic research across findings from different cognition tests is needed to further assess the generalizability of our findings in the future.

This study highlights the moderate to large deficits in cognition among those with TRD and in the older adult population. In particular, moderate to large deficits were found (1) in the domains of executive function, memory, and attention among patients with TRD and (2) in the domains of memory and attention in older patients with MDD. These findings extend to the earlier study reported by Rock and his colleagues [9]. Because impaired cognitive functioning in MDD is associated with poor response to antidepressant treatment [64, 65] and deteriorated psychosocial functioning [3], pharmacological and psychosocial interventions should be tailored to address cognitive impairment in these subgroup populations.

To date, relatively few interventions have been shown to improve cognitive functioning in MDD [66, 67]. Pharmacological interventions have mixed findings. While one meta-analysis suggested that antidepressants, particularly SSRIs, may improve multiple domains of cognition in adults with MDD [68], some studies [69, 70] suggested differential effects of antidepressants on cognition, requiring further research. Furthermore, use of antidepressants and/or other psychotropic medications should be carefully considered since the medications themselves can have detrimental effects on cognitive performance due in part to withdrawal symptoms and/or other iatrogenic factors (e.g., extrapyramidal side effects affecting cognitive disturbances) [71]. Cognition-oriented non-pharmacological interventions (e.g., cognitive-behavioral therapy and cognitive remediation therapy) are also found to show promising results for improving cognitive impairment in MDD [69, 72]. Because cognitive deficits may even persist in remission from MDD [25] or result in other neurodegenerative disorders (e.g., ADRD [11, 12]), both alleviation of depressive symptoms and remediation of cognitive impairment should be prioritized when treating individuals with MDD.

There are several limitations in our study. First, included studies had relatively small sample sizes, which may have undermined the internal or external validity of studies. However, we did not detect any publication bias in our meta-analysis, and methodological quality assessment of individual studies was considered “good.” Second, while we attempted to control for and/or identify potential moderators in our meta-regression analyses (online suppl. eTable 3), it was not possible to control for other possible confounders (e.g., early or late onset of illness, duration of illness, number of episodes, and psychotic features) due to insufficient data reported in individual studies. Third, we only had two studies focusing on children [55, 60], and in particular, children’s executive function was different from findings from other subgroups. It is clinically important to note potential heterogeneity across subpopulations, and more studies are needed using the CANTAB measures to assess cognitive functioning among children with MDD in order to compare or contrast with findings from a previous study [14]. Furthermore, the number of effect sizes was not always sufficient in our subgroup analyses (e.g., 2 studies in reaction time in Fig. 3a), and interpretations should account for this potential limitation.

In conclusion, this study demonstrates that patients with MDD are likely to have significant, moderate cognitive deficits when compared to healthy subjects. Further, some subpopulation groups (e.g., those with TRD or older adults with MDD) are likely to have greater effect sizes of cognitive deficits. Because cognitive impairment can persist in remission or lead to other neurodegenerative disorders (e.g., ADRD), remediation of cognitive impairment in addition to alleviation of depressive symptoms should be an important goal when treating patients with MDD.

An ethics statement is not applicable because this study is based exclusively on published literature. Written informed consent was not required as this study is based exclusively on published literature.

Each author completed and submitted the ICMJE Form for Disclosure of Potential Conflicts of Interest and had none directly related to this manuscript. Rhee was supported in part by the National Institute on Aging (NIA) (#R21AG070666; R21AG078972), the National Institute of Mental Health (#R21MH117438), the National Institute on Drug Abuse (#R21DA057540), and the Institute for Collaboration on Health, Intervention, and Policy (InCHIP) of the University of Connecticut. Dr. Rhee serves as a review committee member for Patient-Centered Outcomes Research Institute (PCORI) and Substance Abuse and Mental Health Services Administration (SAMHSA) and has received honoraria payments from PCORI and SAMHSA. Dr. Rhee has also served as a stakeholder/consultant for PCORI and received consulting fees from PCORI. Dr. Rhee serves as an advisory committee member for International Alliance of Mental Health Research Funders (IAMHRF). Dr. Rhee is currently a co-editor-in-chief of Mental Health Science and has received honorarium payments annually from the publisher, John Wiley & Sons, Inc. Shim, Kaster, D’Andrea, and Steffens reported none. Manning has received research grant funding from the National Institute of Mental Health (#K21MH118420) and the Alzheimer’s Association. He serves as a consultant for Brandywine Assisted Living. Tennen was supported in part by the National Institute on Alcohol Abuse and Alcoholism (NIAAA) (#P50AA027055 and #T32AA00729) and by the National Institute of Dental and Craniofacial Research (NIDCR) (#U01DE028520). He serves as a consultant to Yale University School of Medicine (NIAAA #R01AA026844) for which he receives a consulting fee. Dr. Tennen is the editor of the Journal of Personality and receives honorarium payments annually from the publisher, John Wiley & Sons, Inc. Forester has received research grant funding from Biogen, Eisai, Rogers Family Foundation, Spier Family Foundation, and the NIH. He also serves in the Pharmacy and Therapeutics Committee for CVS Health and is a consultant for Patina Health and Rippl Care. Nierenberg is supported by grants from the Patient-Centered Outcomes Research Institute (PaCR-2017C2-8169, XPPRN-1512-33786, XPPRN-1512-33786), the Thomas P. Hackett, MD Endowed Chair in Psychiatry at MGH, and the Dauten Family Center for Bipolar Treatment Innovation. Nierenberg is a consultant for Abbott Laboratories, Alkermes, American Psychiatric Association, Appliance Computing Inc., Mindsite, Basilea, BrainCells Inc., Brandeis University, Bristol-Myers Squibb, Clintara, Corcept, Dey Pharmaceuticals, Dainippon Sumitomo (now Sunovion), Eli Lilly, Epiq, Mylan, Forest, Genaissance, Genentech, GlaxoSmithKline, Hoffmann-La Roche, Infomedics, Intra-Cellular Therapies, Lundbeck, Janssen Pharmaceutical, Jazz Pharmaceuticals, MedAvante, Merck, Methylation Sciences, Naurex, NeuroRx, Novartis, Otsuka, Pamlabs, Parexel, Pfizer, PGx Health, Ridge Diagnostics Shire, Schering-Plough, Somerset, Sunovion, Takeda Pharmaceuticals, Targacept, and Teva; consulted through the Massachusetts General Hospital Clinical Trials Network and Institute for AstraZeneca, BrainCells Inc., Dainippon Sumitomo/Sepracor, Johnson and Johnson, LaboPharm, Merck, Methylation Science, Novartis, PGx Health, Shire, Schering-Plough, Targacept, and Takeda/Lundbeck Pharmaceuticals; receives grant or research support from American Foundation for Suicide Prevention, Agency for Healthcare Research and Quality, Brain and Behavior Research Foundation, Bristol-Myers Squibb, Cederroth, Cephalon, Cyberonics, Elan, Eli Lilly, Forest, GlaxoSmithKline, Janssen Pharmaceutical, Intra-Cellular Therapies, Lichtwer Pharma, Marriott Foundation, Mylan, National Institute of Mental Health, Pamlabs, Patient-Centered Outcomes Research Institute, Pfizer, Shire, Stanley Foundation, Takeda, and Wyeth-Ayerst; honoraria include Belvoir Publishing, University of Texas Southwestern Dallas, Brandeis University, Bristol-Myers Squibb, Hillside Hospital, American Drug Utilization Review, American Society for Clinical Psychopharmacology, Baystate Medical Center, Columbia University, Controlled Risk Insurance Company, Dartmouth Medical School, Health New England, Harold Grinspoon Charitable Foundation, Imedex, Israel Society for Biological Psychiatry, Johns Hopkins University, MJ Consulting, New York State, Medscape, MBL Communications Inc., Massachusetts General Hospital Psychiatry Academy, National Association of Continuing Education, Physicians Postgraduate Press, State University of New York Buffalo, University of Wisconsin, University of Pisa, University of Michigan, University of Miami, University of Wisconsin at Madison, World Congress of Brain Behavior and Emotion, American Professional Society of ADHD and Related Disorders, International Society for Bipolar Disorder, SciMed, Slack Publishing, Wolters Kluwer Publishing, the American Society for Clinical Psychopharmacology (formerly NCDEU), Rush Medical College, Yale University School of Medicine, National Nuclear Data Center, Nova Southeastern University, National Alliance on Mental Illness, Institute of Medicine, Continued Medical Education Institute, and the International Society for CNS Clinical Trials and Methodology; is currently or was formerly on the advisory boards of Appliance Computing Inc., BrainCells Inc., Eli Lilly, Genentech, Johnson and Johnson, Takeda/Lundbeck, Targacept, and Infomedics; owns stock options in Appliance Computing Inc., BrainCells Inc., and MedAvante; has copyrights to the Clinical Positive Affect Scale and the Massachusetts General Hospital Structured Clinical Interview for the Montgomery Asberg Depression Scale exclusively licensed to the Massachusetts General Hospital Clinical Trials Network and Institute.McIntyre has received research grant support from CIHR/GACD/National Natural Science Foundation of China (NSFC); speaker/consultation fees from Lundbeck, Janssen, Alkermes, Mitsubishi, Tanabe, Purdue, Pfizer, Otsuka, Takeda, Neurocrine, Sunovion, Bausch Health, Axsome, Novo Nordisk, Kris, Sanofi, Eisai, Intra-Cellular, NewBridge Pharmaceuticals, AbbVie, Atai Life Sciences. Dr. Roger McIntyre is a CEO of Braxia Scientific Corp.

This study received no funding.

Study concept, design, and supervision: Rhee; data acquisition, statistical analyses, and drafting of the manuscript: Rhee and Shim; and interpretation of data and critical revision of the manuscript for important intellectual content: Rhee, Shim, Manning, Tennen, Kaster, d’Andrea, Forester, Nierenberg, McIntyre, and Steffens. Rhee had full access to all the data in the study and takes responsibility for the integrity of the data and the accuracy of the data analysis.

Drs. Rhee and Shim are the co-first authors.PROSPERO Registration: #CRD42023433574.

Data are publicly available. All data generated or analyzed during this study are included in this article. Further inquiries can be directed to the corresponding author.