Suppose you are the developer of a new therapy for a mental health problem or you have several years of experience working with such a therapy, and you would like to prove that it is effective. Randomised trials have become the gold standard to prove that interventions are effective, and they are used by treatment guidelines and policy makers to decide whether or not to adopt, implement or fund a therapy.

You would want to do such a randomised trial to get your therapy disseminated, but in reality your clinical experience already showed you that the therapy works. How could you do a trial in order to optimise the chance of finding a positive effect?

Methods that can help include a strong allegiance towards the therapy, anything that increases expectations and hope in participants, making use of the weak spots of randomised trials (risk of bias), small sample sizes and waiting list control groups (but not comparisons with existing interventions). And if all that fails one can always not publish the outcomes and wait for positive trials.

Several methods are available to help you show that your therapy is effective, even when it is not.

Previous mental health surveys conducted in prisons within emerging countries recruited samples of all prisoners at any single point in time. However, this sampling strategy results in an overrepresentation of long-term prisoners as compared with those studies recruiting from all admissions over time. This study aimed to assess mental disorders in consecutively admitted prisoners soon after admission, in order to address service needs of people with short-term imprisonments and people at early stages of imprisonment.

Disorders were assessed in a sample of 229 male and 198 female prisoners, consecutively committed to the penal justice system in Santiago de Chile, using the structured Mini-Neuropsychiatric interview. Prevalence rates were calculated as per cent values. Ninety-five per cent confidence intervals were calculated for the proportions.

Illicit drug and/or alcohol use disorders in the year prior to admission were present in 173 (76%) male and 64 (32%) female prisoners. The substances most frequently causing addiction were cocaine-based products in 108 (47%) male and 42 (21%) female prisoners. Current major depression was present in 124 (54%) male and 86 (43%) female prisoners, and current non-affective psychotic disorders in 18 (8%) male and in 10 (5%) female prisoners. High suicidal risk was present in 64 (28%) male prisoners and in 29 (15%) female prisoners.

When consecutive prisoners are assessed at admission, rates of mental health and substance use disorders were higher than in previous studies in emerging countries that had sampled from all existing prisoners at a time. Affective disorders and suicide risk appear more prevalent than in admission studies conducted in Western high-income countries. Previous research may have systematically underestimated the extent of mental health problems in prisoners, which poses a major public health challenge in emerging countries.

Sexual minorities experience excess psychological ill health globally, yet the UK data exploring reasons for poor mental health among sexual minorities is lacking. This study compares the prevalence of a measure of well-being, symptoms of common mental disorder (CMD), lifetime suicidal ideation, harmful alcohol and drug use among inner city non-heterosexual and heterosexual individuals. It is the first UK study which aims to quantify how much major, everyday and anticipated discrimination; lifetime and childhood trauma; and coping strategies for dealing with unfair treatment, predict excess mental ill health among non-heterosexuals. Further, inner city and national outcomes are compared.

Self-report survey data came from the South East London Community Health study (N = 1052) and the Adult Psychiatric Morbidity Survey (N = 7403).

Adjustments for greater exposure to measured experiences of discrimination and lifetime and childhood trauma had a small to moderate impact on effect sizes for adverse health outcomes though in fully adjusted models, non-heterosexual orientation remained strongly associated with CMD, lifetime suicidal ideation, harmful alcohol and drug use. There was limited support for the hypothesis that measured coping strategies might mediate some of these associations. The inner city sample had poorer mental health overall compared with the national sample and the discrepancy was larger for non-heterosexuals than heterosexuals.

Childhood and adult adversity substantially influence but do not account for sexual orientation-related mental health disparities. Longitudinal work taking a life course approach with more specific measures of discrimination and coping is required to further understand these associations. Sexual minorities should be considered as a priority in the design and delivery of health and social services.

Despite the considerable physical, emotional and social change that occurs during emerging adulthood, there is little research that examines the association between having a chronic health condition and mental disorder during this developmental period. The aims of this study were to examine the sex-specific prevalence of lifetime mental disorder in an epidemiological sample of emerging adults aged 15–30 years with and without chronic health conditions; quantify the association between chronic health conditions and mental disorder, adjusting for sociodemographic and health factors; and, examine potential moderating and mediating effects of sex, level of disability and pain.

Data come from the Canadian Community Health Survey-Mental Health. Respondents were 15–30 years of age (n = 5947) and self-reported whether they had a chronic health condition. Chronic health conditions were classified as: respiratory, musculoskeletal/connective tissue, cardiovascular, neurological and endocrine/digestive. The World Health Organization Composite International Diagnostic Interview 3.0 was used to assess the presence of mental disorder (major depressive disorder, suicidal behaviour, bipolar disorder and generalised anxiety disorder).

Lifetime prevalence of mental disorder was significantly higher for individuals with chronic health conditions compared with healthy controls. Substantial heterogeneity in the prevalence of mental disorder was found in males, but not in females. Logistic regression models adjusting for several sociodemographic and health factors showed that the individuals with chronic health conditions were at elevated risk for mental disorder. There was no evidence that the level of disability or pain moderated the associations between chronic health conditions and mental disorder. Sex was found to moderate the association between musculoskeletal/connective tissue conditions and bipolar disorder (β = 1.71, p = 0.002). Exploratory analyses suggest that the levels of disability and pain mediate the association between chronic health conditions and mental disorder.

Physical and mental comorbidity is prevalent among emerging adults and this relationship is not augmented, but may be mediated, by the level of disability or pain. Findings point to the integration and coordination of public sectors – health, education and social services – to facilitate the prevention and reduction of mental disorder among emerging adults with chronic health conditions.

Recent research has shown an association between unemployment and suicide, but the mediating factors in this relationship are still unknown. In this study, we investigated the effect of unemployment and economic recession on suicide rates in the Spanish region of Galicia between 1975 and 2012

We analysed age-standardised suicide rates in men and women and in four age groups: less than 25 years, 25–45 years, 45–65 years and more than 65 years and performed a joinpoint analysis to determine trend changes throughout 1975–2012 period. Also we analysed the association between suicide, recession and unemployment by means of a temporal trend model with a Generalised Additive Model.

Suicide rates increased from 145 suicides in 1975 to a high in 1993, with 377 deaths by suicide, representing 1.38% of all causes of death, and thereafter they tend to decrease to 335 suicides in 2012. Joinpoint analyses revealed that suicide rates changed differently across sex and age groups. For men, the annual percentage of change (APC) between 1975 and 1988 (CI 95% 1986–1994) was 5.45 (CI 95% = 3.5, −7.2) but from 1988 the APC became negative [−0.66 (CI 95% = −1.3, −0.1)]. For women, APC between 1974 and 1990 (CI 95% 1986–1992) was 4.86 (CI 95% = 3.2, −6.4) and −1.46 subsequently (CI 95% = −2.2, −0.5). Women aged 24 years or less showed stable suicide rates while men from 45–65 years showed two incidence peaks. When we studied the independent correlation between unemployment, recession and suicide, we found a significant association between unemployment and suicide, but not between recession and suicide for both sexes together and for men while for women there was no significant correlation between suicide and unemployment or recession. Finally, when we studied the effect of the interaction between unemployment and recession on suicide we found economic recession and unemployment interacted with regards to suicide rates (F = 5.902; df = 4.167; p = 0.00098) and after adjusting by sex, the effect was confirmed among men (F = 4.827; df = 2.823; p = 0.0087), but not among women (F = 0.001; df = 1.000; p = 0.979).

Although suicide rates in Galicia are gradually decreasing in the last decades, there are important sex and age differences. Unemployment was related with suicide during economic recession periods according to our results.

Many instruments have been developed and validated to assess the stigma associated with mental disorders and its various domains across different populations. To our knowledge, the Reported and Intended Behaviour Scale (RIBS) is the only validated questionnaire to analyse the presence of reported and intended stigmatising/discriminatory behaviours towards people with mental health problems in the general population. The aims of the study presented herein are to translate and validate the RIBS in Italian language and to adapt it to the Italian socio-cultural background (RIBS-I).

The RIBS considers reported and intended behaviours across four different domains: (1) living with, (2) working with, (3) living nearby and (4) continuing a relationship with someone with a mental health problem. The validation process included four phases: (1) translation/back translation of the questionnaire from English to Italian and vice versa; (2,3) face validity and reliability of RIBS-I; (4) description of model fit through confirmatory factor analysis. The questionnaire was administered to a sample of the general public via distribution in public places such as shopping centres, markets, squares, cinemas and other gathering places. Questionnaires were administered by trained mental health professionals.

A total of 447 lay respondents were recruited. The mean age was 38.08 (s.d. = ±14.74) years. Fifty-seven per cent of the sample (n = 257) were female. The Cronbach alpha of RIBS-I was 0.83. All indices of model fit were above the reference values: Goodness of Fit Index (GFI) = 0.987 (GFI > 0.9); Adjusted Goodness of Fit Index (AGFI) = 0.975 (AGFI > 0.9); Comparative Fit Index (CFI) = 0.994 (CFI > 0.9); and Root-Mean-Square Error of Approximation (RMSEA) = 0.023 (RMSEA < 0.05). The χ2 = 23.60 (df = 19; p = 0.21) and χ2/df = 1.24 supported the model.

The RIBS-I demonstrated good psychometric properties and it can be considered a useful tool to: (1) assess stigmatising (actual or potential) behaviours in the general population; (2) test the efficacy of anti-stigma campaigns and actions; (3) design further studies to better understand the relationship between the three different components of stigmatisation: knowledge, attitudes and behaviours.