Psychotic disorders, including schizophrenia (SZ), schizoaffective disorder (SZA), bipolar disorder (BD), psychotic depression (PD), and other nonaffective psychoses (ONAP), are associated with increased risk of suicidal acts. Few studies have compared suicidal act prevalence across psychotic disorders using both self-report and register data. The impact of hospitalization duration on subsequent suicidal acts is unclear.

We used data from the SUPER-Finland study, involving 7067 participants with register-based ICD-10 diagnoses of psychotic disorders (SZ, SZA, BD, PD, ONAP). Lifetime suicidal acts were identified through self-report and register-based records of intentional self-harm events requiring medical treatment. Associations between diagnostic categories and suicidal acts were assessed using logistic regression, adjusted for sex, duration of illness, socioeconomic status, childhood abuse, and substance use. Survival analysis was used to examine the impact of hospital stay length on postdischarge self-harm.

Lifetime suicide attempts (39.1%) and register self-harm (19.3%) were prevalent. of those with self-reported suicide attempts, 40.5% also had register-based self-harm. Self-harm and suicide attempts were significantly more prevalent in SZA, BD, and PD compared to schizophrenia, with large differences between groups (24.1–46.4% for suicide attempts, 11.1–23.9% for self-harm). Adjusted odds of self-harm were higher for disorders with a mood component. Shorter hospitalizations were associated with an elevated hazard ratio for subsequent self-harm.

Prevalence of register-based self-harm and self-reported suicide attempts differ markedly. Suicidal acts are common in psychotic disorders, particularly in those with a mood component. Very short inpatient stays may not be adequate in these disorders.

Completed suicide (CS) is among the leading causes of death. Suicide attempts (SAs) are more frequent and are a significant contributor to overall morbidity. However, there is only few data on community-based suicide prevention using systemic approaches. We have implemented a communal suicide prevention program and tested whether it reduced the number of SA and CS.

“FraPPE” comprised measures proposed by previous studies: low-threshold outpatient services, a SA postvention, a hotline targeting individuals with suicidal intent, qualification of gatekeepers and general practitioners, and a campaign to refer SA cases to psychiatric services and antistigma campaigns. The intervention lasted for 25 months.

For CS, 7.7 cases per month were recorded during baseline, compared to 9 cases per month in the intervention phase. For SA, the numbers were 39.2 and 40.7, respectively. These numbers did not differ significantly. The most frequent diagnostic group was affective disorders, followed by substance use disorders. The average age was lower in the SA group. More males committed suicide (p < 0.001), whereas the sex ratio was balanced in SA.

The communal suicide prevention measures implemented in FraPPE did not reduce the number of suicides and SAs. This should be interpreted with caution, as a number of prevention measures were already executed in the region. Also, data were confounded by the COVID-19 pandemic. Our awareness campaign may also have reduced the dark field, leading to increased reporting. We thus propose to enact registries on suicidal behaviors, to obtain better data and develop new preventive measures.

Adolescents are at a heightened risk of suicide reattempts following hospital discharge, but few evidence-based interventions exist. This study evaluated the efficacy of the self-awareness of mental health (SAM) program combined with treatment as usual (TAU) versus TAU alone in reducing reattempts among high-risk adolescents.

A randomized clinical trial was conducted across nine Spanish hospitals (January 2021–March 2024) with 261 adolescents (12–17 years) who had attempted suicide within the last 15 days. Participants were assigned to SAM + TAU (n=128) or TAU (n=133), with 12-month follow-up. The primary outcome was suicide reattempts within 12 months; secondary analyses examined time to reattempt and associated risk factors.

After 12-months, no significant differences were found in reattempt rates [22.6% (SAM) versus 27.8% (TAU); OR=0.610, 95%CI (0.321–1.151), p=0.127] or time to reattempt [HR=0.606, 95%CI (0.390–1.021), p=0.060]. In SAM, attentional impulsivity emerged as a significant risk factor [HR=1.126, 95% CI (1.004–1.263), p=0.043], while nonplanning impulsivity was protective [HR=0.878, 95%CI (0.814–0.948), p<0.001]. In TAU, increased suicide risk was linked to suicidal intentionality [HR=1.341, 95%CI (1.009–1.782), p=0.044] and more prior attempts [HR=1.230, 95%CI (1.039–1.457), p=0.016]. Conversely, fewer psychiatric diagnoses emerged as a protective factor [HR=0.821, 95%CI (0.677–0.996), p=0.045].

While no significant differences were found between groups, SAM identified important psychological factors influencing suicide risk. These findings provide a foundation for targeted interventions to prevent reattempts in adolescents.

The neurobiological basis of suicidal behaviour remains poorly understood. However, emerging evidence suggests that inflammation and vascular homeostasis factors may play a role in its pathophysiology. Childhood trauma, through immune system dysfunction and increased risk of suicidal behaviours, might influence these associations. This study examined the relationships between immune-inflammatory and vascular homeostasis-related markers and their interaction with childhood trauma in relation to a history of suicide attempts in individuals with depression.

A total of 328 patients with major depression were recruited: 166 with a history of suicide attempts and 162 without. Using multivariate binary logistic regression models adjusted for cofounders, we examined the associations between childhood trauma, levels of platelet-related immune markers (serotonin, MCP-1, TSP-1, TSP-2, PDGF-AB, PDGF-BB), and suicide attempt history. Independent associations between PDGF-BB, childhood trauma, and suicide attempts were further assessed using interaction models. Stratified sensitivity analyses based on childhood trauma history were also conducted.

Childhood trauma consistently emerged as associated with suicide attempts across all models. Among the measured biomarkers, higher TSP-2 levels were associated with a suicide attempt history, independent of childhood trauma. Meanwhile, while PDGF-BB alone was not directly linked to suicide attempt history, the interaction analysis revealed that individuals with lower PDGF-BB levels and more severe childhood trauma were more likely to have attempted suicide.

TSP-2 and PDGF-BB are potential biomarkers linked to suicide attempts, with distinct roles in the interplay between biological processes and early-life adversity. These insights can inform the biomarker-informed development of tailored prevention and treatment strategies.

This study examines the prospective associations of alcohol and drug misuse with suicidal behaviors among service members who have left active duty. We also evaluate potential moderating effects of other risk factors and whether substance misuse signals increased risk of transitioning from thinking about to attempting suicide.

US Army veterans and deactivated reservists (N = 6,811) completed surveys in 2016–2018 (T1) and 2018–2019 (T2). Weights-adjusted logistic regression was used to estimate the associations of binge drinking, smoking/vaping, cannabis use, prescription drug abuse, illicit drug use, alcohol use disorder (AUD), and drug use disorder (DUD) at T1 with suicide ideation, plan, and attempt at T2. Interaction models tested for moderation of these associations by sex, depression, and recency of separation/deactivation. Suicide attempt models were also fit in the subgroup with ideation at T1 (n = 1,527).

In models controlling for socio-demographic characteristics and prior suicidality, binge drinking, cannabis use, prescription drug abuse, illicit drug use, and AUD were associated with subsequent suicidal ideation (AORs = 1.42–2.60, ps < .01). Binge drinking, AUD, and DUD were associated with subsequent suicide plan (AORs = 1.23–1.95, ps < .05). None of the substance use variables had a main effect on suicide attempt; however, interaction models suggested certain types of drug use predicted attempts among those without depression. Additionally, the effects of smoking/vaping and AUD differed by sex. Substance misuse did not predict the transition from ideation to attempt.

Alcohol and drug misuse are associated with subsequent suicidal behaviors in this population. Awareness of differences across sex and depression status may inform suicide risk assessment.

Previous studies investigating the effectiveness of augmentation therapy have been limited.

To evaluate the effectiveness of antipsychotic augmentation therapies among patients with treatment-resistant depression.

We included patients diagnosed with depression receiving two antidepressant courses within 1 year between 2009 and 2020 and used the clone-censor-weight approach to address time-lag bias. Participants were assigned to either an antipsychotic or a third-line antidepressant. Primary outcomes were suicide attempt and suicide death. Cardiovascular death and all-cause mortality were considered as safety outcomes. Weighted pooled logistic regression and non-parametric bootstrapping were used to estimate approximate hazard ratios and 95% confidence intervals.

The cohort included 39 949 patients receiving antipsychotics and the same number of matched antidepressant patients. The mean age was 51.2 (standard deviation 16.0) years, and 37.3% of participants were male. Compared with patients who received third-line antidepressants, those receiving antipsychotics had reduced risk of suicide attempt (sub-distribution hazard ratio 0.77; 95% CI 0.72–0.83) but not suicide death (adjusted hazard ratio 1.08; 95% CI 0.93–1.27). After applying the clone-censor-weight approach, there was no association between antipsychotic augmentation and reduced risk of suicide attempt (hazard ratio 1.06; 95% CI 0.89–1.29) or suicide death (hazard ratio 1.22; 95% CI 0.91–1.71). However, antipsychotic users had increased risk of all-cause mortality (hazard ratio 1.21; 95% CI 1.07–1.33).

Antipsychotic augmentation was not associated with reduced risk of suicide-related outcomes when time-lag bias was addressed; however, it was associated with increased all-cause mortality. These findings do not support the use of antipsychotic augmentation in patients with treatment-resistant depression.

Borderline personality disorder (BPD) is a debilitating condition characterized by pervasive instability across multiple major domains of functioning. The majority of persons with BPD engage in self-injury and up to 10% die by suicide – rendering persons with this condition at exceptionally elevated risk of comorbidity and premature mortality. Better characterization of clinical risk factors among persons with BPD who die by suicide is urgently needed.

We examined patterns of medical and psychiatric diagnoses (1580 to 1700 Phecodes) among persons with BPD who died by suicide (n = 379) via a large suicide death data resource and biobank. In phenotype-based phenome-wide association tests, we compared these individuals to three other groups: (1) persons who died by suicide without a history of BPD (n = 9468), (2) persons still living with a history of BPD diagnosis (n = 280), and (3) persons who died by suicide with a different personality disorder (other PD n = 589).

Multivariable logistic regression models revealed that persons with BPD who died by suicide were more likely to present with co-occurring psychiatric diagnoses, and have a documented history of self-harm in the medical system prior to death, relative to suicides without BPD. Posttraumatic stress disorder was more elevated among those with BPD who died by suicide relative to the other PD group.

We found significant differences among persons with BPD who died by suicide and all other comparison groups. Such differences may be clinically informative for identifying high-risk subtypes and providing targeted intervention approaches.

Suicidal behavior constitutes a multi-cause phenomenon that may also be present in people without a mental disorder. This study aims to analyze suicidal behavior outcomes in a sample of attempters, from a symptom-based approach.

The sample comprised 673 patients (72% female; M = 40.9 years) who attended a hospital emergency department due to a suicide attempt. A wide range of clinical factors (e.g., psychopathology symptoms, psychiatric diagnoses, impulsivity, acquired capability), was administered within 15 days after the index attempt. Nine psychopathology domains were explored to identify the profile of symptoms, using latent profile analysis. The relationship between the profile membership and suicide outcome (i.e., intensity of suicidal ideation, number of suicide behaviors, and medical injury derived from index attempt) was also studied, using linear and logistic regression.

Three psychopathology profiles were identified: high-symptom profile (45.02% of participants), moderate-symptom profile (42.50%), and low-symptom profile (12.48%). High-symptom profile members were more likely to show higher risk of non-suicidal self-injury, acquired capability for suicide, and more severe suicide behavior and ideation. On the other hand, a more severe physical injury was associated with low-symptom profile membership in comparison to membership from the other profiles (OR < 0.45, p < .05).

A symptom-based approach may be useful to monitor patients and determine the risk of attempt repetition in the future and potential medical injury, and to optimize prevention and intervention strategies.

While previous studies have reported high rates of documented suicide attempts (SAs) in the U.S. Army, the extent to which soldiers make SAs that are not identified in the healthcare system is unknown. Understanding undetected suicidal behavior is important in broadening prevention and intervention efforts.

Representative survey of U.S. Regular Army enlisted soldiers (n = 24 475). Reported SAs during service were compared with SAs documented in administrative medical records. Logistic regression analyses examined sociodemographic characteristics differentiating soldiers with an undetected SA v. documented SA. Among those with an undetected SA, chi-square tests examined characteristics associated with receiving a mental health diagnosis (MH-Dx) prior to SA. Discrete-time survival analysis estimated risk of undetected SA by time in service.

Prevalence of undetected SA (unweighted n = 259) was 1.3%. Annual incidence was 255.6 per 100 000 soldiers, suggesting one in three SAs are undetected. In multivariable analysis, rank ⩾E5 (OR = 3.1[95%CI 1.6–5.7]) was associated with increased odds of undetected v. documented SA. Females were more likely to have a MH-Dx prior to their undetected SA (Rao-Scott χ 21 = 6.1, p = .01). Over one-fifth of undetected SAs resulted in at least moderate injury. Risk of undetected SA was greater during the first four years of service.

Findings suggest that substantially more soldiers make SAs than indicated by estimates based on documented attempts. A sizable minority of undetected SAs result in significant injury. Soldiers reporting an undetected SA tend to be higher ranking than those with documented SAs. Undetected SAs require additional approaches to identifying individuals at risk.

Late-life suicide is the most serious consequences of late-life depression (LLD). Nevertheless, suicidal behavior is complex and hard to predict. With the help of MRI scans and machine learning algorithm, we aim to examine the neural signatures of suicidality in patients of LLD.

We recruited 83 patients of LLD with a mean age of 68.8 years, where 48 were suicidal (26 with suicidal ideation and 22 with past suicide attempts). Cross-sample entropy (CSE) analysis was employed to analyze the resting-state function MRI data. Three-dimensional CSE volume in 90 region-of-interest of the brain in each participant was input into convolutional neural networks (CNN) to test the classification accuracy of suicidality.

After six-fold cross-validation, we found several regions in the default mode, fronto-parietal, and cingulo-opercular resting-state networks to have a mean accuracy above 75% to predict suicidality. Moreover, the models with right amygdala and left caudate provided the most reliable accuracy in all cross-validation folds, signifying their unique roles in late-life suicide.

Our results provide potential targets for intervention or biomarkers in late-life suicide. More research must be conducted to consolidate our results with scalable implementation in clinical setting.

Prior research has reported an association between divorce and suicide attempt. We aimed to clarify this complex relationship, considering sex differences, temporal factors, and underlying etiologic pathways.

We used Swedish longitudinal national registry data for a cohort born 1960–1990 that was registered as married between 1978 and 2018 (N = 1 601 075). We used Cox proportional hazards models to estimate the association between divorce and suicide attempt. To assess whether observed associations were attributable to familial confounders or potentially causal in nature, we conducted co-relative analyses.

In the overall sample and in sex-stratified analyses, divorce was associated with increased risk of suicide attempt (adjusted hazard ratios [HRs] 1.66–1.77). Risk was highest in the year immediately following divorce (HRs 2.20–2.91) and declined thereafter, but remained elevated 5 or more years later (HRs 1.41–1.51). Divorcees from shorter marriages were at higher risk for suicide attempt than those from longer marriages (HRs 3.33–3.40 and 1.20–1.36, respectively). In general, HRs were higher for divorced females than for divorced males. Co-relative analyses suggested that familial confounders and a causal pathway contribute to the observed associations.

The association between divorce and risk of suicide attempt is complex, varying as a function of sex and time-related variables. Given evidence that the observed association is due in part to a causal pathway from divorce to suicide attempt, intervention or prevention efforts, such as behavioral therapy, could be most effective early in the divorce process, and in particular among females and those whose marriages were of short duration.

Little is known about when youth may be at greatest risk for attempting suicide, which is critically important information for the parents, caregivers, and professionals who care for youth at risk. This study used adolescent and parent reports, and a case-crossover, within-subject design to identify 24-hour warning signs (WS) for suicide attempts.

Adolescents (N = 1094, ages 13 to 18) with one or more suicide risk factors were enrolled and invited to complete bi-weekly, 8–10 item text message surveys for 18 months. Adolescents who reported a suicide attempt (survey item) were invited to participate in an interview regarding their thoughts, feelings/emotions, and behaviors/events during the 24-hours prior to their attempt (case period) and a prior 24-hour period (control period). Their parents participated in an interview regarding the adolescents’ behaviors/events during these same periods. Adolescent or adolescent and parent interviews were completed for 105 adolescents (81.9% female; 66.7% White, 19.0% Black, 14.3% other).

Both parent and adolescent reports of suicidal communications and withdrawal from social and other activities differentiated case and control periods. Adolescent reports also identified feelings (self-hate, emotional pain, rush of feelings, lower levels of rage toward others), cognitions (suicidal rumination, perceived burdensomeness, anger/hostility), and serious conflict with parents as WS in multi-variable models.

This study identified 24-hour WS in the domains of cognitions, feelings, and behaviors/events, providing an evidence base for the dissemination of information about signs of proximal risk for adolescent suicide attempts.

Insecure attachment styles are associated with retrospectively reported suicide attempts (SAs). It is not known if attachment styles are prospectively associated with medically documented SAs.

A representative sample of US Army soldiers entering service (n = 21 772) was surveyed and followed via administrative records for their first 48 months of service. Attachment style (secure, preoccupied, fearful, dismissing) was assessed at baseline. Administrative medical records identified SAs. Discrete-time survival analysis examined associations of attachment style with future SA during service, adjusting for time in service, socio-demographics, service-related variables, and mental health diagnosis (MH-Dx). We examined whether associations of attachment style with SA differed based on sex and MH-Dx.

In total, 253 respondents attempted suicide. Endorsed attachment styles included secure (46.8%), preoccupied (9.1%), fearful (15.7%), and dismissing (19.2%). Examined separately, insecure attachment styles were associated with increased odds of SA: preoccupied [OR 2.5 (95% CI 1.7–3.4)], fearful [OR 1.6 (95% CI 1.1–2.3)], dismissing [OR 1.8 (95% CI 1.3–2.6)]. Examining attachment styles simultaneously along with other covariates, preoccupied [OR 1.9 (95% CI 1.4–2.7)] and dismissing [OR 1.7 (95% CI 1.2–2.4)] remained significant. The dismissing attachment and MH-Dx interaction was significant. In stratified analyses, dismissing attachment was associated with SA only among soldiers without MH-Dx. Other interactions were non-significant. Soldiers endorsing any insecure attachment style had elevated SA risk across the first 48 months in service, particularly during the first 12 months.

Insecure attachment styles, particularly preoccupied and dismissing, are associated with increased future SA risk among soldiers. Elevated risk is most substantial during first year of service but persists through the first 48 months. Dismissing attachment may indicate risk specifically among soldiers not identified by the mental healthcare system.

Prior self-harm represents the most significant risk factor for future self-harm or suicide.

To evaluate the cost-effectiveness of a theoretical brief aftercare intervention (involving brief follow-up contact, care coordination and safety planning), following a hospital-treated self-harm episode, for reducing repeated self-harm within the Australian context.

We employed economic modelling techniques to undertake: (a) a return-on-investment analysis, which compared the cost-savings generated by the intervention with the overall cost of implementing the intervention; and (b) a cost–utility analysis, which compared the net costs of the intervention with health outcomes measured in quality-adjusted life years (QALYs). We considered cost offsets associated with hospital admission for self-harm and the cost of suicide over a period of 10 years in the base case analysis. Uncertainty and one-way sensitivity analyses were also conducted.

The brief aftercare intervention resulted in net cost-savings of AUD$7.5 M (95% uncertainty interval: −56.2 M to 15.1 M) and was associated with a gain of 222 (95% uncertainty interval: 45 to 563) QALYs over a 10-year period. The estimated return-on-investment ratio for the intervention's modelled cost in relation to cost-savings was 1.58 (95% uncertainty interval: −0.17 to 5.33). Eighty-seven per cent of uncertainty iterations showed that the intervention could be considered cost-effective, either through cost-savings or with an acceptable cost-effectiveness ratio of 50 000 per QALY gained. The results remained robust across sensitivity analyses.

A theoretical brief aftercare intervention is highly likely to be cost-effective for preventing suicide and self-harm among individuals with a history of self-harm.

Few population-based studies have compared the mental health of gender minority and cisgender adolescents.

To compare reports of psychological distress, behavioural and emotional difficulties, self-harm and suicide attempts between gender minority and cisgender adolescents.

Data came from the Millennium Cohort Study (n = 10 247), a large nationally representative birth cohort in the UK. At a 17-year follow-up, we assessed gender identity, psychological distress (Kessler K6 scale), behavioural and emotional difficulties (parent and child reports on the Strengths and Difficulties Questionnaire), self-harm in the previous year, suicide attempts, substance use, and victimisation including harassment and physical and sexual assaults. Multivariable modified Poisson and linear regression models were used. Attenuation after the inclusion of victimisation and substance use was used to explore mediation.

Of the 10 247 participants, 113 (1.1%) reported that they were a gender minority. Gender minority participants reported more psychological distress (coefficient 5.81, 95% CI 4.87–6.74), behavioural and emotional difficulties (child report: coefficient 5.60; 95% CI 4.54–6.67; parent/carer report: coefficient 2.60; 95% CI 1.47–3.73), self-harm including cutting or stabbing (relative risk (RR) 4.38; 95% CI 3.55–5.40), burning (RR 3.81; 95% CI 2.49–5.82), taking an overdose (RR 5.25; 95% CI 3.35–8.23) and suicide attempts (RR 3.42; 95% CI 2.45–4.78) than cisgender youth. These associations were partially explained by differences in exposure to victimisation.

Gender minority adolescents experience a disproportionate burden of mental health problems. Policies are needed to reduce victimisation and services should be adapted to better support the mental health of gender minority adolescents.

Risk of suicide-related behaviors is elevated among military personnel transitioning to civilian life. An earlier report showed that high-risk U.S. Army soldiers could be identified shortly before this transition with a machine learning model that included predictors from administrative systems, self-report surveys, and geospatial data. Based on this result, a Veterans Affairs and Army initiative was launched to evaluate a suicide-prevention intervention for high-risk transitioning soldiers. To make targeting practical, though, a streamlined model and risk calculator were needed that used only a short series of self-report survey questions.

We revised the original model in a sample of n = 8335 observations from the Study to Assess Risk and Resilience in Servicemembers-Longitudinal Study (STARRS-LS) who participated in one of three Army STARRS 2011–2014 baseline surveys while in service and in one or more subsequent panel surveys (LS1: 2016–2018, LS2: 2018–2019) after leaving service. We trained ensemble machine learning models with constrained numbers of item-level survey predictors in a 70% training sample. The outcome was self-reported post-transition suicide attempts (SA). The models were validated in the 30% test sample.

Twelve-month post-transition SA prevalence was 1.0% (s.e. = 0.1). The best constrained model, with only 17 predictors, had a test sample ROC-AUC of 0.85 (s.e. = 0.03). The 10–30% of respondents with the highest predicted risk included 44.9–92.5% of 12-month SAs.

An accurate SA risk calculator based on a short self-report survey can target transitioning soldiers shortly before leaving service for intervention to prevent post-transition SA.