The aim of this study was to reanalyse the data from Cuijpers et al.'s (2018) meta-analysis, to examine Eysenck's claim that psychotherapy is not effective. Cuijpers et al., after correcting for bias, concluded that the effect of psychotherapy for depression was small (standardised mean difference, SMD, between 0.20 and 0.30), providing evidence that psychotherapy is not as effective as generally accepted.

The data for this study were the effect sizes included in Cuijpers et al. (2018). We removed outliers from the data set of effects, corrected for publication bias and segregated psychotherapy from other interventions. In our study, we considered wait-list (WL) controls as the most appropriate estimate of the natural history of depression without intervention.

The SMD for all interventions and for psychotherapy compared to WL controls was approximately 0.70, a value consistent with past estimates of the effectiveness of psychotherapy. Psychotherapy was also more effective than care-as-usual (SMD = 0.31) and other control groups (SMD = 0.43).

The re-analysis reveals that psychotherapy for adult patients diagnosed with depression is effective.

Suicidal behaviour is prevalent among adolescents and is a significant predictor of future suicide attempts (SAs) and suicide death. Data on the prevalence and epidemiological characteristics of suicidal behaviour in Chinese adolescents are limited. This study was aimed to examine the prevalence, characteristics and risk factors of suicidal behaviour, including suicidal thought (ST), suicide plan (SP) and SA, in a large sample of Chinese adolescents.

This report represents the first wave data of an ongoing longitudinal study, Shandong Adolescent Behavior and Health Cohort. Participants included 11 831 adolescent students from three counties of Shandong, China. The mean age of participants was 15.0 (s.d. = 1.5) and 51% were boys. In November–December 2015, participants completed a structured adolescent health questionnaire, including ST, SP and SA, characteristics of most recent SA, demographics, substance use, hopelessness, impulsivity and internalising and externalising behavioural problems.

The lifetime and last-year prevalence rates were 17.6 and 10.7% for ST in males, 23.5 and 14.7% for ST in females, 8.9 and 2.9% for SP in males, 10.7 and 3.8% for SP in females, 3.4 and 1.3% for SA in males, and 4.6 and 1.8% for SA in females, respectively. The mean age of first SA was 12–13 years. Stabbing/cutting was the most common method to attempt suicide. Approximately 24% of male attempters and 16% of female attempters were medically treated. More than 70% of attempters had no preparatory action. Female gender, smoking, drinking, internalising and externalising problems, hopelessness, suicidal history of friends and acquaintances, poor family economic status and poor parental relationship were all significantly associated with increased risk of suicidal behaviour.

Suicidal behaviour in Chinese adolescents is prevalent but less than that previously reported in Western peers. While females are more likely to attempt suicide, males are more likely to use lethal methods. Multiple child and family factors are associated with suicidal behaviour. These findings highlight the importance of early screening and intervention of suicidal behaviour in Chinese adolescents.

Suicide-related behaviours are common in schizophrenia and are significantly associated with premature death. The objective of this meta-analysis study was to estimate the pooled prevalence of suicide-related behaviours in schizophrenia patients in China.

The relevant literature was searched systematically via the relevant electronic databases (PubMed, Embase, PsycINFO, Chinese National Knowledge Infrastructure, Wanfang Databases and Chinese Biological Medical Literature Database) from their inception until 14 September 2016. Only original studies that reported the prevalence of suicide-related behaviours including suicidal ideation (SI), suicide plan, suicide attempt (SA) and completed suicide were selected.

Nineteen articles met the inclusion criteria and were analysed. The pooled lifetime prevalence of SI and SA were 25.8% (95% CI 14.7–41.1%) and 14.6% (95% CI 9.1–22.8%), respectively. The 1-month prevalence of SI was 22.0% (95% CI 18.2–26.4%). Subgroup analyses of lifetime SI and SA showed that gender, sample size, survey year, study location and source of patients have no significant mediating effects on the results.

Suicide-related behaviours are common in Chinese schizophrenia patients. Due to the high mortality risk, regular screening and effective suicide prevention programmes are warranted.

We have previously reported an association between childhood abuse and psychotic experiences (PEs) in survey data from South East London. Childhood abuse is related to subsequent adulthood adversity, which could form one pathway to PEs. We aimed to investigate evidence of mediation of the association between childhood abuse and PEs by adverse life events.

Data were analysed from the South East London Community Health Study (SELCoH, n = 1698). Estimates of the total effects on PEs of any physical or sexual abuse while growing up were partitioned into direct (i.e. unmediated) and indirect (total and specific) effects, mediated via violent and non-violent life events.

There was strong statistical evidence for direct (OR 1.58, 95% CI: 1.19–2.1) and indirect (OR 1.51, 95% CI: 1.32–1.72) effects of childhood abuse on PEs after adjustment for potential confounders, indicating partial mediation of this effect via violent and non-violent life events. An estimated 47% of the total effect of abuse on PEs was mediated via adulthood adverse life events, of which violent life events made up 33% and non-violent life events the remaining 14%.

The association between childhood abuse and PEs is partly mediated through the experience of adverse life events in adulthood. There is some evidence that a larger proportion of this effect was mediated through violent life events than non-violent life events.

To examine the lifetime prevalence and risk of psychiatric disorders associated with natural and man-made disaster exposure in Australia.

We utilised data from a nationally representative population survey (N = 8841) which were analysed through univariate and multivariate logistic regression in order to examine the full spectrum of Diagnostic and Statistical Manual of Mental Disorders, Fourth Edition (DSM-IV) affective, anxiety and substance use disorders associated with exposure to natural and man-made disaster.

Man-made disaster exposure was primarily associated with an increased lifetime risk (odds ratio (95% CI)) of alcohol abuse disorder 2.29 (1.56–3.37), post-traumatic stress disorder (PTSD) 2.27 (1.36–3.79), obsessive–compulsive disorder (OCD) 1.95 (1.08–3.51) and major depressive disorder 1.69 (1.01–2.85). Multiple natural disaster exposure was associated with an increased lifetime risk of panic disorder 2.26 (1.11–4.61). Among the broader disorder spectrum examined, alcohol abuse disorder accounted for the single greatest increase in lifetime disorder prevalence associated with man-made disaster exposure, and the greatest number of natural or man-made disaster exposed individuals who had developed a lifetime psychiatric disorder. Despite the relatively greater disorder risk associated with man-made disaster, natural disaster exposure was associated with more cases of psychiatric disorder, likely due to the frequency with which these events occur in Australia.

Notwithstanding the inability to draw causal inferences from cross-sectional survey data, population-based analyses provide a comprehensive and consistent method to ascertain the population imprint of psychiatric disorder and disaster exposure. Mental health policy and services should be targeting a range of psychiatric disorders in disaster contexts in addition to the usual focus on PTSD and depression, including alcohol abuse, panic disorder and OCD. Despite the relatively greater disorder risk associated with man-made disaster exposure, the national burden of psychiatric disorder in natural disaster contexts is particularly high.

Although associations between various somatic diseases and depression are well established, findings concerning the role of gender and anxiety disorders for these associations remain fragmented and partly inconsistent. Combining data from three large-scaled epidemiological studies in primary care, we aim to investigate interactions of somatic diseases with gender and anxiety disorders in the association with depression.

Self-reported depression according to the International Classification of Diseases, Tenth Edition (ICD-10) was assessed in n = 83 737 patients from three independent studies [DETECT (Diabetes Cardiovascular Risk Evaluation: Targets and Essential Data for Commitment of Treatment), Depression-2000 and Generalized Anxiety and Depression in Primary Care (GAD-P)] using the Depression Screening Questionnaire (DSQ). Diagnoses of depression, anxiety disorders and somatic diseases were obtained from treating physicians via standardised clinical appraisal forms.

In logistic regressions, adjusted for gender, age group and study, each somatic disease except for arterial hypertension and endocrine diseases was associated with self-reported depression (odds ratio, OR 1.3–2.6) and each somatic disease was associated with physician-diagnosed depression (OR 1.1–2.4). Most of these associations remained significant after additional adjustment for anxiety disorders and other somatic diseases. The associations with depression increased with a higher number of somatic diseases. Cardiovascular diseases (OR 0.8), diabetes mellitus (OR 0.8) and neurological diseases (OR 0.8) interacted with gender in the association with self-reported depression, while endocrine diseases (OR 0.8) interacted with gender in the association with physician-diagnosed depression. That is, the associations between respective somatic diseases and depression were less pronounced in females v. males. Moreover, cardiovascular diseases (OR 0.7), arterial hypertension (OR 0.8), gastrointestinal diseases (OR 0.7) and neurological diseases (OR 0.6) interacted with anxiety disorders in the association with self-reported depression, and each somatic disease interacted with anxiety disorders in the association with physician-diagnosed depression (OR 0.6–0.8). That is, the associations between respective somatic diseases and depression were less pronounced in patients with v. without anxiety disorders; arterial hypertension was negatively associated with self-reported depression only in patients with anxiety disorders, but not in patients without anxiety disorders.

A range of somatic diseases as well as anxiety disorders are linked to depression – and especially patients with co-/multi-morbidity are affected. However, interactions with gender and anxiety disorders are noteworthy and of relevance to potentially improve recognition and treatment of depression by physicians. Somatic diseases are associated more strongly with depression in males v. females as well as in patients without v. with anxiety disorders, primarily because women and patients with anxiety disorders per se are characterised by considerably increased depression prevalence that only marginally changes in the presence of somatic comorbidity.

After the diagnosis of immune-mediated inflammatory diseases (IMID) such as inflammatory bowel disease (IBD), multiple sclerosis (MS) and rheumatoid arthritis (RA), the incidence of psychiatric comorbidity is increased relative to the general population. We aimed to determine whether the incidence of psychiatric disorders is increased in the 5 years before the diagnosis of IMID as compared with the general population.

Using population-based administrative health data from the Canadian province of Manitoba, we identified all persons with incident IBD, MS and RA between 1989 and 2012, and cohorts from the general population matched 5 : 1 on year of birth, sex and region to each disease cohort. We identified members of these groups with at least 5 years of residency before and after the IMID diagnosis date. We applied validated algorithms for depression, anxiety disorders, bipolar disorder, schizophrenia, and any psychiatric disorder to determine the annual incidence of these conditions in the 5-year periods before and after the diagnosis year.

We identified 12 141 incident cases of IMID (3766 IBD, 2190 MS, 6350 RA) and 65 424 matched individuals. As early as 5 years before diagnosis, the incidence of depression [incidence rate ratio (IRR) 1.54; 95% CI 1.30–1.84) and anxiety disorders (IRR 1.30; 95% CI 1.12–1.51) were elevated in the IMID cohort as compared with the matched cohort. Similar results were obtained for each of the IBD, MS and RA cohorts. The incidence of bipolar disorder was elevated beginning 3 years before IMID diagnosis (IRR 1.63; 95% CI 1.10–2.40).

The incidence of psychiatric comorbidity is elevated in the IMID population as compared with a matched population as early as 5 years before diagnosis. Future studies should elucidate whether this reflects shared risk factors for psychiatric disorders and IMID, a shared final common inflammatory pathway or other aetiology.

The aims of this study were to investigate the effects of either hearing, vision or dual sensory impairment on depressive symptoms and to identify subgroups that are vulnerable and significantly affected.

Data from the 2006–2014 Korean Longitudinal Study of Aging (KLoSA) were used and a total of 5832 individuals were included in this study. Depressive symptoms were assessed using the Center for Epidemiologic Studies Depression (CES-D10) scale. Sensory impairment was assessed according to the levels of self-reported hearing or vision, which were categorised as either good (excellent, very good or good) or poor (fair or poor). The changes in hearing or vision from records of previous survey were investigated. Changes from good to poor, which indicates new onset, were defined as hearing impairment or vision impairment. Interactions of changes in hearing and vision were considered in the analysis. Dual sensory impairment was indicated when hearing impairment and vision impairment both developed at the same time. Demographic, socioeconomic and health-related factors were considered as potential confounders and were adjusted for in the generalised estimating equation model.

Individuals with hearing impairment demonstrated significantly more severe depressive symptoms [β = 0.434, standard errors (s.e.) = 0.097, p < 0.001] than those who had good hearing. Those with vision impairment also showed significantly elevated depressive symptoms (β = 0.253, s.e. = 0.058, p < 0.001) than those with good vision. When the interactions between hearing and vision were considered, participants with dual sensory impairment showed significantly more severe depressive symptoms (β = 0.768, s.e. = 0.197, p < 0.001) than those with good hearing and vision. The effect of a single and dual sensory impairment on depressive symptoms was significant in both sexes and across age groups, except for vision impairment in male participants.

Hearing, vision and dual sensory impairment are significantly associated with depressive symptoms. Our results suggest that treatment or rehabilitation of either hearing or vision impairment would help prevent depression.