There has been little research into the facilitated discharge (FD) function of Home Treatment Teams (HTTs). We aimed to explore and describe the prevalence and associations of FD and to estimate its effects on bed days during the index admission (length of stay corrected for ward leave) and on readmission.

Descriptive and regression analyses of data collected by South London and Maudsley NHS Foundation Trust on discharges from its general psychiatric wards, with multiple imputation of missing covariate values.

Overall, 29% of our sample of 7891 hospital admissions involved a FD. FD was associated with female gender, diagnosis of a severe mental illness, previous home treatment, having a longer previous admission, neither being discharged to a new address nor to a care home, having no other community team and having HoNOS item scores consistent with an active depressive or psychotic mental illness. In the regression analysis, FD was associated with 4.0 fewer bed days (95% confidence interval −6.7 to −1.3; p = 0.0004). There was no effect on readmission.

Our analysis provides some support for the effectiveness of FD in slightly reducing the time spent in hospital and suggests that this may be achieved without increasing the rate of readmission. Further studies in this area are important, especially given existing research that suggests that the introduction of HTTs in England and Wales was associated with little or no change in service utilisation.

Seasonal as well as weekly cycles in suicide have been described, replicated and poorly understood for a long time. In Western countries, suicides are typically least frequent on weekends and most frequent on Mondays and Tuesdays. To improve understanding of this phenomenon a strategy is required which focuses on anomalous findings beyond the regular patterns. Here, we focused on instances where the weekly suicide patterns disappear or are interrupted.

We used data from Swiss and Austrian mortality statistics for the periods 1969–2010 and 1970–2010, respectively. First, the data were cross-tabulated by days of the week and the available socio-demographic information (sex, age, religious affiliation and region). Second, time series of cumulated daily frequencies of suicide were analysed by seasonal Autoregressive Integrated Moving Average (ARIMA) models which included intervention effects accounting for Easter and Pentecost (Whit) holidays.

First, the cross tabulations showed that weekly cycles may be smoothed above all in young persons and smoothed in drowning, jumping and car gas exhaustion suicides. Second, the ARIMA analyses displayed occasional preventive effects for holidays Saturdays and Sundays, and more systematic effects for holiday Mondays. There were no after effects on Tuesdays following holiday Mondays.

In general, the weekend dip and the Monday backlog effect in suicide show striking similarities to the Advent season effect and are interpretable within the same template. The turning points between low and high frequencies possibly provide promising frames for the timing of prevention activities.

To date, very few studies have examined the bi-directional associations between mood disorders (MDs), anxiety disorders (ADs) and substance use disorders (SUDs), simultaneously. The aims of the current study were to determine the rates and patterns of comorbidity of the common MDs, ADs and SUDs and describe the onset and temporal sequencing of these classes of disorder, by sex.

Data came from the 2007 Australian National Survey of Mental Health and Wellbeing, a nationally representative household survey with 8841 (60% response rate) community residents aged 16–85.

Pre-existing mental disorders increase the risk of subsequent mental disorders in males and females regardless of the class of disorder. Pre-existing SUDs increase the risk of subsequent MDs and ADs differentially for males and females. Pre-existing MDs increase the risk of subsequent ADs differentially for males and females.

Comorbidity remains a significant public health issue and current findings point to the potential need for sex-specific prevention and treatment responses.

To study whether employees who disclose a psychiatric diagnosis, such as depression risk stigmatisation and discrimination at the workplace.

Randomised experimental study with 748 managers from German companies incorporating four case vignettes displaying an employee with different ‘diagnoses’ (depression, burnout, private crisis and thyroid dysfunction), but identical unspecific complaints. Main outcome measures were the managers' attitudes and their impact on stigmatisation with respect to job performance.

In nearly all aspects of job performance, the diagnosis depression (psychiatric disorder) was seen as more critical than the diagnosis of a thyroid dysfunction (somatic disease). The diagnosis ‘burnout’ did not prove to be less stigmatising than ‘depression’. Likewise ‘private crisis’ was rated less favourably than thyroid dysfunction.

Therefore, employees have to evaluate if they disclose their psychiatric disorder or if they conceal it as a somatic illness.

An inherent prerequisite to mental health first-aid (MHFA) is the ability to identify that there is a mental health problem, but little is known about the association between psychiatric labelling and MHFA. This study examined this association using data from two national surveys of Australian young people.

This study involved a national telephonic survey of 3746 Australian youth aged 12–25 years in 2006, and a similar survey in 2011 with 3021 youth aged 15–25 years. In both surveys, respondents were presented with a vignette portraying depression, psychosis or social phobia in a young person. The 2011 survey also included depression with suicidal thoughts and post-traumatic stress disorder. Respondents were asked what they thought was wrong with the person, and reported on their first-aid intentions and beliefs, which were scored for quality of the responses.

Accurate labelling of the mental disorder was associated with more helpful first-aid intentions and beliefs across vignettes, except for the intention to listen non-judgementally in the psychosis vignette.

Findings suggest that community education programmes that improve accurate psychiatric label use may have the potential to improve the first-aid responses young people provide to their peers, although caution is required in the case of psychosis.

Self-report questionnaires are frequently used in clinical and epidemiologic studies to assess post-traumatic stress disorder (PTSD). A number of studies have evaluated these scales relative to clinician administered structured interviews; however, there has been no formal evaluation of their performance relative to non-clinician administered epidemiologic assessments such as the Composite International Diagnostic Interview (CIDI). We examined the diagnostic performance of two self-report PTSD scales, the PTSD checklist (PCL) and the Vietnam Era Twin Registry (VET-R) PTSD scale, compared to the CIDI.

Data were derived from a large epidemiologic follow-up study of PTSD in 5141 Vietnam Era Veterans. Measures included the PCL, VET-R PTSD scale and CIDI. For both the PCL and VET-R PTSD scale, ROC curves, areas under the curve (AUC), sensitivity, specificity, % correctly classified, likelihood ratios, predictive values and quality estimates were generated based on the CIDI PTSD diagnosis.

For the PCL and VET-R PTSD scale the AUCs were 89.0 and 87.7%, respectively. Optimal PCL cutpoints varied from the 31–33 range (when considering sensitivity and specificity) to the 36–56 range (when considering quality estimates). Similar variations were found for the VET-R PTSD, ranging from 31 (when considering sensitivity and specificity) to the 37–42 range (when considering quality estimates).

The PCL and VET-R PTSD scale performed similarly using a CIDI PTSD diagnosis as the criterion. There was a range of acceptable cutpoints, depending on the metric used, but most metrics suggested a lower PCL cutpoint than in previous studies in Veteran populations.

There is ample evidence media reporting of celebrity suicides increases copycat suicides. This study had three aims: (a) to quantitatively examine copycat suicides with exponential modelling that predicts the copycat suicide effect of South Korean celebrity suicides; (b) to investigate the association between media effect and subsequent suicides following celebrity deaths; and (c) to investigate the extent in which media influences the increase and rate of decline of copycat suicides following a celebrity suicide.

All suicides during 1991–2010 in South Korea were included in this study utilising a nationwide database. Fifteen celebrities were selected based on the frequency of media reports following 1 week after their suicide. The media effect was obtained through the Korean Integrated Newspaper Database System. Exponential curve fits and correlation analyses investigated the quantitative effect of copycat suicides.

After controlling for baseline number of average suicides, there was a marked increase in the number of suicides following each celebrity suicides, which followed an exponential model. There was a significant correlation between the total number of copycat suicides and number of media following the celebrity suicide (r = 0.74, p < 0.01). There were weak-to-moderate correlations between the amplitude of increase in suicides (r = 0.45, p = 0.09) and rate of decline (r = 0.38, p = 0.16) with the total number of media coverage.

Copycat suicides following celebrity suicides follow exponential modelling. Additionally, there is a strong media effect between the number of media reports following the days after celebrity suicides and subsequent copycat suicides. This may also be associated with the amplitude and rate of decline of copycat suicides. This suggests that improving media reporting and implementing preventative interventions for vulnerable populations may be important.

This study aims to examine Queensland suicide trends in the Australian-born population and in the overseas-born populations over the past 2 decades.

All suicide cases for the period 1991–2009 were identified in the Queensland Suicide Register. Age-standardised suicide rates were calculated. Joinpoint regression and Poisson regression were applied.

A significant decline in suicide rates of young (15–44 years) overseas-born males was reported over the past 2 decades. Australian-born young males showed significant increase until 1996, followed by a significant decline; furthermore, their suicide rates were significantly higher when compared to overseas-born (RR = 1.36, 95%CI: 1.15; 1.62). Contrary older Australian-born males (45+ years) had significantly lower suicide rates than overseas-born males (RR = 0.90, 95%CI: 0.83; 0.98). Despite the convergence of the suicide trends for older males, changes were not significant. While Australian-born females had a significant increase in suicides, overseas-born females had a decline in 1991–2009.

Conclusion. Significantly declining suicide rates of migrants have contributed to the declining in suicide trends in Queensland. Potential reasons for significantly lower suicide rates among young migrants might include the change in the nature of migration from involuntary to voluntary.