Approximating defense mechanisms in a national study of adults: prevalence and correlates with functioning.

Despite the clinical relevance of defense mechanisms, there are no published studies in nationally representative samples of their prevalence, correlates, and association with psychosocial functioning. We sought to estimate the prevalence and correlates of 12 defense mechanisms in the general adult population by approximating from items used to assess personality traits in the National Epidemiological Survey on Alcohol and Related Conditions (NESARC), a representative sample of US adults (N = 36,653). We examined the associations between sociodemographic characteristics and prevalence of 3 types of defenses mechanisms (pathological, immature, and neurotic). For each defense mechanism, we used the Short-Form 12 to compare psychosocial functioning among 3 groups: those who (1) endorsed the mechanism with self-recognized impairment, (2) endorsed the mechanism without self-recognized impairment, and (3) did not endorse the defense mechanism. The prevalence of defense mechanisms ranged from 13.2% (splitting) to 44.5% (obsessive/controlling behavior). Pathological defenses were more strongly associated with immature defenses (OR = 5.4, 95% CI = 5.2-5.6) than with neurotic defenses (OR = 2.0, 95% CI = 1.9-2.0), whereas the association between immature and neurotic defenses had an intermediate value between the other two (OR = 2.2, 95% CI = 2.1-2.2). Pathological and immature defenses were associated with younger age, having been never married, lower educational attainment, and lower income. After adjusting the crude results for age and sex, individuals who did not endorse a given defense generally had higher scores on the mental health component of the SF-12 than those who endorsed the defense without self-recognized impairment who, in turn, had on average higher scores than those with self-recognized impairment. These results suggest that neurotic, immature, and pathological defense mechanisms are prevalent in the general population and associated with psychosocial impairment. Recognizing defense mechanisms may be important in clinical practice regardless of treatment modality.

Adolescents With Attention-Deficit/Hyperactivity Disorder: Adverse Behaviors and Comorbidity.

PURPOSE AND OBJECTIVE: There is growing evidence that adolescents with ADHD develop long-term impairments and adverse outcomes, yet less is known about their adverse behaviors. To quantify rates of mental health comorbidities in adolescents with ADHD and compare the risks of adverse behaviors among adolescents with and without ADHD. METHODS: We performed a cohort analysis of 6,483 youth from the National Comorbidity Survey Adolescent Supplement (NCS-A), a nationally representative in-person structured diagnostic interview of adolescents aged 14-18 years focusing on mental, emotional, and behavioral disorders. MAIN OUTCOMES: (1) Percentages with comorbid anxiety, mood, disruptive behavior, and substance use disorders. (2) Strength of associations of ADHD with several adverse behaviors, including suicidal symptoms, aggression, behavior regulation, life events, education, and substance use. Odds ratios were adjusted for age, sex, and race. RESULTS: Among the sample of 6,483 adolescents, overall, 9.5% met the criteria for ADHD. Most (69.5%) of adolescents with ADHD had at least one comorbid mental health condition. As compared to adolescents without ADHD, those with ADHD were significantly more likely to have had a suicide attempt (aOR 2.9, 95% CI = 1.3-6.6) and to have had perpetrated physical aggression (aOR 2.3, 95% CI = 1.7-3.2). Adolescents with ADHD were also more likely to have been expelled from school or fired from a job (aOR 3.3, 95% CI = 1.7-6.5) and to have had problems related to drinking alcohol (95% CI = 1.2-2.9). CONCLUSIONS: ADHD in adolescents is a complicated disorder with elevated risks for a wide range of adverse behaviors.

Psychiatric disorders and risk for multiple adverse outcomes: a national prospective study.

Most psychiatric disorders, when examined individually, are associated with a broad range of adverse outcomes. However, psychiatric disorders often co-occur and their co-occurrence is well explained by a limited number of transdiagnostic factors. Yet it remains unclear whether the risk of these adverse outcomes is due to specific psychiatric disorders, specific dimensions of psychopathology (i.e., internalizing and externalizing dimensions), a general psychopathology factor, or a combination of these explanations. In a large nationally representative prospective survey, the National Epidemiologic Survey on Alcohol and Related Conditions (NESARC), we used structural equation modeling to examine the shared and specific effects of common Axis I and Axis II disorders on the risk of ten adverse outcomes (unemployment; financial crisis; low income; poorer general health; worse mental and physical health; legal problems; divorce; problems with a neighbor, friend, or relative; and violence) in the general adult population. Effects of psychiatric disorders were exerted mostly through a general psychopathology factor representing the shared effect across all disorders, independent of sociodemographic characteristics and the presence of the adverse outcomes at baseline. Violence and legal problems were further associated with the externalizing factor, but there were no independent associations of the internalizing factor or any individual psychiatric disorders with any of the adverse outcomes. Our findings reveal that associations between psychiatric disorders and adverse outcomes occur through broad psychological dimensions. Understanding the biological and psychological mechanisms underlying these dimensions should yield key intervention targets to decrease the individual suffering and societal burden associated with common psychiatric disorders.

Sex differences on the relation between major depressive disorder and labor market outcomes: A national prospective study.

To ascertain the direction of causality and differences by sex between major depressive disorder (MDD) and labor market outcomes in the US population, we used structural equation models separately for males and females to assess prospectively the interdependency of depression and labor market outcomes at Waves 1 (2001-2002) and 2 (2004-2005) of the National Epidemiologic Survey on Alcohol and Related Conditions. Diagnosis of MDD used DSM-IV criteria. We found that MDD at Wave 1 predicted being out of the labor force for males at Wave 2 (p = 0.006) and being in the labor force at Wave 1 was associated with lower probability of MDD at Wave 2 (p = 0.049). Among males in the labor force, MDD at Wave 1 was negatively associated with employment at Wave 2 (p = 0.047), and employment at Wave 1 was negatively associated with MDD at Wave 2 (p < 0.001). For women, there was no association between MDD and labor force participation. However, among women in the labor force, MDD at Wave 1 was negatively associated with employment at Wave 2 (p = 0.013) and being employed at Wave 1 was negatively associated with MDD at Wave 2 (p < 0.0001). These results indicate that MDD and negative labor market outcomes are associated with one another at both time points, but the effects differ by sex. To reduce the economic and social burden of MDD, these differences should be considered in clinical practice, vocational rehabilitation, and in the design of social policies.

Toward a Comprehensive Developmental Model of Prescription Opioid Use Disorder.

OBJECTIVE: To develop a comprehensive etiologic model of DSM-5 prescription opioid use disorder (POUD) based on Kendler and colleagues' development model for major depressive disorder. METHODS: Data were drawn from the National Epidemiologic Survey on Alcohol and Related Conditions-III (2012-2013). Risk factors were divided into 4 developmental tiers (childhood/early adolescence, late adolescence, adulthood, past year). Hierarchical logistic regression models were used to examine the independent contribution of each risk factor. Separate models were built to predict 12-month nonmedical use of prescription opioids and risk of POUD among those with 12-month nonmedical use. RESULTS: After adjustment for other risk factors, the odds of past 12-month nonmedical use of prescription opioids were increased by history of trauma, social deviance, and use of drugs other than opioids in adulthood and by past-year pain, alcohol use disorder (AUD), tobacco use disorder, any Axis I disorder other than SUD, and number of stressful events. History of POUD in adulthood and pain, AUD, tobacco use disorder, and any Axis I disorder other than substance use disorders (SUD) in the past year increased the odds of 12-month POUD. History of SUD other than POUD in adulthood was associated with lower odds of POUD. For both outcomes, the effect of earlier development tiers was mediated by more proximal ones. CONCLUSIONS: A modification of Kendler and colleagues' model for major depressive disorder provides a useful foundation for a comprehensive developmental model of nonmedical opioid use and opioid use disorder.

Treatment of Common Mental Disorders in the United States: Results From the National Epidemiologic Survey on Alcohol and Related Conditions-III.

OBJECTIVE: This study analyzed past 12-month disorder-specific mental health treatment patterns of common DSM-5 disorders in the United States. METHODS: Nationally representative face-to-face household survey data from structured diagnostic interviews of the 2012-2013 National Epidemiologic Survey on Alcohol and Related Conditions-III (NESARC-III) (n = 36,309) were used to estimate percentages of respondents with 12-month DSM-5 mood, anxiety, and substance use disorders who received disorder-specific treatment during the 12 months before the interview. RESULTS: The percentage receiving treatment was highest for mood disorders (37.8%; 95% CI, 36.1%-39.6%), followed by anxiety disorders (24.1%; 95% CI, 22.6%-25.6%), and lowest for substance use disorders (18.8%; 95% CI, 17.8%-19.8%). Among anxiety disorders, panic disorder (47.9%; 95% CI, 43.9%-52.0%) had the highest treatment rate, and among substance use disorders, tobacco use disorder (20.3%; 95% CI, 19.0%-21.7%) had the highest treatment rate. Adults with mood and anxiety disorders (53.1%; 95% CI, 49.7%-56.4%) were more likely than those with only mood (32.0%; 95% CI, 29.5%-34.6%) or only anxiety (13.2%; 95% CI, 11.6%-15.0%) disorders to receive any mental health treatment. Lack of insurance coverage was associated with significantly lower odds of treatment for all disorders except specific phobia (0.55; 95% CI, 0.30-1.03), drug use disorders other than tobacco (0.80; 95% CI, 0.47-1.36), and alcohol use disorder (1.52; 95% CI, 1.12-2.07). CONCLUSIONS: Most adults with common mental disorders in the United States were not treated for their disorders, and treatment rates varied considerably across disorders and sociodemographic groups, with particularly low rates of treatment for substance use disorders. Policy and clinical interventions are needed to promote greater access to treatment of adults with common substance use, anxiety, and mood disorders.

E-cigarette Use Among Young Adults in the U.S.

INTRODUCTION: Use of e-cigarettes is increasing among young adults in the U.S. Whether e-cigarette use serves as an aid to smoking reduction or cessation among young adults remains a matter of contention. This analysis examines patterns of e-cigarette use in relation to cigarette smoking in a nationally representative sample of U.S. young adults. METHODS: Data were analyzed from nationally representative U.S. adults, aged 18 to 35years (N=12,415), in the 2012-2013 National Epidemiologic Survey on Alcohol and Related Conditions-III. Logistic regression assessed associations between e-cigarette use and smoking intensity, continuity, and reduction while controlling for several potential confounding factors. Data were analyzed in 2018. RESULTS: Among cigarette smokers, e-cigarette use was associated with higher odds of tobacco use disorder (AOR=2.58, 95% CI=1.73, 3.83) and daily cigarette smoking (AOR=1.67, 95% CI=1.73, 3.83). Among adults aged 26-35years, e-cigarette use was also associated with heavy cigarette smoking (AOR=2.01, 95% CI=1.09, 3.74). Among lifetime smokers, e-cigarette use was associated with lower odds of stopping smoking (AOR=0.14, 95% CI=0.08, 0.23) and lower odds of a 50% reduction in cigarettes smoked per day (AOR=0.63, 95% CI=0.43, 0.93). Only 13.1% of young adults who ever used e-cigarettes reported using them to help stop or quit smoking. CONCLUSIONS: Use of e-cigarettes by U.S. young adults, most of which is not intended to help reduce smoking, is related to more rather than less frequent and intensive cigarette smoking.

Insomnia and Impaired Quality of Life in the United States.

OBJECTIVE: This analysis characterizes the individual-level and population-level burden of insomnia in relation to other medical conditions and describes the comorbidity of insomnia with other medical conditions, including the dependence of these comorbidities on pain, life events, and mental disorders. METHODS: Information from 34,712 adults in the National Epidemiologic Survey on Alcohol and Related Conditions-III (2012-2013) was analyzed. Quality-adjusted life-years (QALYs) were measured with the SF-6D, a 6-dimensional health state classification derived from the Short-Form-12, version 2. RESULTS: In the last 12 months, 27.3% of adults reported insomnia. The US annual loss of QALYs associated with insomnia (5.6 million; 95% CI, 5.33-5.86 million) was significantly larger than that associated with any of the other 18 medical conditions assessed, including arthritis (4.94 million; 95% CI, 4.62-5.26 million), depression (4.02 million; 95% CI, 3.87-4.17 million), and hypertension (3.63 million; 95% CI, 3.32-3.93 million). After control for demographic factors, all conditions examined from obesity (adjusted odds ratio [aOR] = 1.25) to mania (aOR = 5.04) were associated with an increased risk of insomnia. Further controlling for pain, stressful life events, and mental disorders decreased the odds of the co-occurrence of insomnia with these conditions. The decrease in insomnia comorbidity associated with pain was greatest for fibromyalgia (31.8%) and arthritis (20.1%); the decrease in insomnia comorbidity associated with life events was greatest for mania (13.4%) and drug use disorders (11.2%); and the decrease in insomnia comorbidity associated with mental disorders was greatest for peptic ulcer disease (11.2%) and liver diseases (11.1%). CONCLUSIONS: Insomnia is prevalent and associated with substantial population-level burden in self-assessed health. The co-occurrence of insomnia with common medical conditions is differentially related to pain and to a lesser extent to stressful life events and mental disorders.

Causes of Death After Nonfatal Opioid Overdose.

Importance: A recent increase in patients presenting with nonfatal opioid overdoses has focused clinical attention on characterizing their risks of premature mortality. Objective: To describe all-cause mortality rates, selected cause-specific mortality rates, and standardized mortality rate ratios (SMRs) of adults during their first year after nonfatal opioid overdose. Design, Setting, and Participants: This US national longitudinal study assesses a cohort of patients aged 18 to 64 years who were Medicaid beneficiaries and experienced nonfatal opioid overdoses. The Medicaid data set included the years 2001 through 2007. Death record information was obtained from the National Death Index. Data analysis occurred from October 2017 to January 2018. Main Outcomes and Measures: Crude mortality rates per 100 000 person-years were determined in the first year after nonfatal opioid overdose. Standardized mortality rate ratios (SMR) were estimated for all-cause and selected cause-specific mortality standardized to the general population with respect to age, sex, and race/ethnicity. Results: The primary cohort included 76 325 adults and 66 736 person-years of follow-up. During the first year after nonfatal opioid overdose, there were 5194 deaths, the crude death rate was 778.3 per 10 000 person-years, and the all-cause SMR was 24.2 (95% CI, 23.6-24.9). The most common immediate causes of death were substance use-associated diseases (26.2%), diseases of the circulatory system (13.2%), and cancer (10.3%). For every cause examined, SMRs were significantly elevated, especially with respect to drug use-associated diseases (SMR, 132.1; 95% CI, 125.6-140.0), HIV (SMR, 45.9; 95% CI, 39.5-53.0), chronic respiratory diseases (SMR, 41.1; 95% CI, 36.0-46.8), viral hepatitis (SMR, 30.6; 95% CI, 22.9-40.2), and suicide (SMR, 25.9; 95% CI, 22.6-29.6), particularly including suicide among females (SMR, 47.9; 95% CI, 39.8-52.3). Conclusions and Relevance: In a US national cohort of adults who had experienced a nonfatal opioid overdose, a marked excess of deaths was attributable to a wide range of substance use-associated, mental health, and medical conditions, underscoring the importance of closely coordinating the substance use, mental health, and medical care of this patient population.

Suicide After Deliberate Self-Harm in Adolescents and Young Adults.

OBJECTIVES: Among adolescents and young adults with nonfatal self-harm, our objective is to identify risk factors for repeated nonfatal self-harm and suicide death over the following year. METHODS: A national cohort of patients in the Medicaid program, aged 12 to 24 years (n = 32 395), was followed for up to 1 year after self-harm. Cause of death information was obtained from the National Death Index. Repeat self-harm per 1000 person-years and suicide deaths per 100 000 person-years were determined. Hazard ratios (HRs) of repeat self-harm and suicide were estimated by Cox proportional hazard models. Suicide standardized mortality rate ratios were derived by comparison with demographically matched general population controls. RESULTS: The 12-month suicide standardized mortality rate ratio after self-harm was significantly higher for adolescents (46.0, 95% confidence interval [CI]: 29.9-67.9) than young adults (19.2, 95% CI: 12.7-28.0). Hazards of suicide after self-harm were significantly higher for American Indians and Alaskan natives than non-Hispanic white patients (HR: 4.69, 95% CI: 2.41-9.13) and for self-harm patients who initially used violent methods (HR: 18.04, 95% CI: 9.92-32.80), especially firearms (HR: 35.73, 95% CI: 15.42-82.79), compared with nonviolent self-harm methods (1.00, reference). The hazards of repeat self-harm were higher for female subjects than male subjects (HR: 1.25, 95% CI: 1.18-1.33); patients with personality disorders (HR: 1.55, 95% CI: 1.42-1.69); and patients whose initial self-harm was treated in an inpatient setting (HR: 1.65, 95% CI: 1.49-1.83) compared with an emergency department (HR: 0.62, 95% CI: 0.55-0.69) or outpatient (1.00, reference) setting. CONCLUSIONS: After nonfatal self-harm, adolescents and young adults were at markedly elevated risk of suicide. Among these high-risk patients, those who used violent self-harm methods, particularly firearms, were at especially high risk underscoring the importance of follow-up care to help ensure their safety.

Declining Health-Related Quality of Life in the U.S.

INTRODUCTION: Despite recent declining mortality of the U.S. population from most leading causes, uncertainty exists over trends in health-related quality of life. METHODS: The 2001-2002 and 2012-2013 National Epidemiologic Surveys on Alcohol and Related Conditions U.S. representative household surveys were analyzed for trends in health-related quality of life (n=79,402). Health-related quality of life was measured with the Short Form-6 Dimension scale derived from the Short Form-12. Changes in mean Short Form-6 Dimension ratings were attributed to changes in economic, social, substance abuse, mental, and medical risk factors. RESULTS: Mean Short Form-6 Dimension ratings decreased from 0.820 (2001-2002) to 0.790 (2012-2013; p<0.0001). In regressions adjusted for age, sex, race/ethnicity, and education, variable proportions of this decline were attributable to medical (21.9%; obesity, cardiac disease, hypertension, arthritis, medical injury), economic (15.6%; financial crisis, job loss), substance use (15.3%; substance use disorder or marijuana use), mental health (13.1%; depression and anxiety disorders), and social (11.2%; partner, neighbor, or coworker problems) risks. In corresponding adjusted models, a larger percentage of the decline in Short Form-6 Dimension ratings of older adults (aged ≥55 years) was attributable to medical (35.3%) than substance use (7.4%) risk factors, whereas the reverse occurred for younger adults (aged 18-24 years; 5.7% and 19.7%) and adults aged 25-44 years (12.7% and 16.3%). CONCLUSIONS: Between 2001-2002 and 2012-2013, there was a significant decline in average quality of life ratings of U.S. adults. The decline was partially attributed to increases in several modifiable risk factors, with medical disorders having a larger role than substance use disorders for older adults but the reverse for younger and middle-aged adults.

Cannabis Use and Risk of Prescription Opioid Use Disorder in the United States.

OBJECTIVE: The authors sought to determine whether cannabis use is associated with a change in the risk of incident nonmedical prescription opioid use and opioid use disorder at 3-year follow-up. METHOD: The authors used logistic regression models to assess prospective associations between cannabis use at wave 1 (2001-2002) and nonmedical prescription opioid use and prescription opioid use disorder at wave 2 (2004-2005) of the National Epidemiologic Survey on Alcohol and Related Conditions. Corresponding analyses were performed among adults with moderate or more severe pain and with nonmedical opioid use at wave 1. Cannabis and prescription opioid use were measured with a structured interview (the Alcohol Use Disorder and Associated Disabilities Interview Schedule-DSM-IV version). Other covariates included age, sex, race/ethnicity, anxiety or mood disorders, family history of drug, alcohol, and behavioral problems, and, in opioid use disorder analyses, nonmedical opioid use. RESULTS: In logistic regression models, cannabis use at wave 1 was associated with increased incident nonmedical prescription opioid use (odds ratio=5.78, 95% CI=4.23-7.90) and opioid use disorder (odds ratio=7.76, 95% CI=4.95-12.16) at wave 2. These associations remained significant after adjustment for background characteristics (nonmedical opioid use: adjusted odds ratio=2.62, 95% CI=1.86-3.69; opioid use disorder: adjusted odds ratio=2.18, 95% CI=1.14-4.14). Among adults with pain at wave 1, cannabis use was also associated with increased incident nonmedical opioid use (adjusted odds ratio=2.99, 95% CI=1.63-5.47) at wave 2; it was also associated with increased incident prescription opioid use disorder, although the association fell short of significance (adjusted odds ratio=2.14, 95% CI=0.95-4.83). Among adults with nonmedical opioid use at wave 1, cannabis use was also associated with an increase in nonmedical opioid use (adjusted odds ratio=3.13, 95% CI=1.19-8.23). CONCLUSIONS: Cannabis use appears to increase rather than decrease the risk of developing nonmedical prescription opioid use and opioid use disorder.

Determining if Borderline Personality Disorder and Bipolar Disorder Are Alternative Expressions of the Same Disorder: Results From the National Epidemiologic Survey on Alcohol and Related Conditions.

OBJECTIVE: To examine whether bipolar disorder and borderline personality disorder represent 2 different disorders or alternative manifestations of the same disorder. METHODS: The data were collected between January 1, 2004, and December 31, 2005. The analyses were conducted between December 21 and December 27, 2010. Exploratory factor analysis (EFA) and confirmatory factor analysis (CFA) were performed on 25 symptoms assessing depression, mania, and borderline personality disorder from the National Epidemiologic Survey on Alcohol and Related Conditions, a large nationally representative sample of the US adult population (N = 34,653). DSM-IV criteria were used for diagnosis of bipolar disorder and borderline personality disorder. RESULTS: A 3-factor solution provided an excellent fit in both the EFA (root mean square error of approximation [RMSEA] = 0.017, comparative fix index [CFI] = 0.997) and the CFA (RMSEA = 0.024, CFI = 0.993). Factor 1 (Borderline Personality Disorder) loaded on all 9 borderline personality disorder symptoms, factor 2 (Depression) loaded on 8 symptoms of depression, and factor 3 (Mania) loaded on 7 symptoms of mania plus the psychomotor agitation item of the depression section. The correlations between the Borderline Personality Disorder and Depression factors (r = 0.328) and between the Borderline Personality Disorder and Mania factors (r = 0.394) were lower than the correlation between Depression and Mania factors (r = 0.538). CONCLUSIONS: A model with 3 positively correlated factors provided an excellent fit for the latent structure of borderline personality disorder and bipolar disorder symptoms. The pattern of pairwise correlations between the 3 factors is consistent with the clinical presentation of 2 syndromes (depression and mania) that can be characterized as a unitary psychiatric entity (bipolar disorder) and a third syndrome (borderline personality disorder) that is often comorbid with bipolar disorder. The findings converge in suggesting that bipolar disorder and borderline personality disorder are overlapping but different pathologies. These findings may serve to inform ongoing efforts to refine the existing psychiatric nosology and to suggest new avenues for etiologic and treatment research.

National Trends in Suicide Attempts Among Adults in the United States.

Importance: A recent increase in suicide in the United States has raised public and clinical interest in determining whether a coincident national increase in suicide attempts has occurred and in characterizing trends in suicide attempts among sociodemographic and clinical groups. Objective: To describe trends in recent suicide attempts in the United States. Design, Setting, and Participants: Data came from the 2004-2005 wave 2 National Epidemiologic Survey on Alcohol and Related Conditions (NESARC) and the 2012-2013 NESARC-III. These nationally representative surveys asked identical questions to 69 341 adults, 21 years and older, concerning the occurrence and timing of suicide attempts. Risk differences adjusted for age, sex, and race/ethnicity (ARDs) assessed trends from the 2004-2005 to 2012-2013 surveys in suicide attempts across sociodemographic and psychiatric disorder strata. Additive interactions tests compared the magnitude of trends in prevalence of suicide attempts across levels of sociodemographic and psychiatric disorder groups. The analyses were performed from February 8, 2017, through May 31, 2017. Main Outcomes and Measures: Self-reported attempted suicide in the 3 years before the interview. Results: With use of data from the 69 341 participants (42.8% men and 57.2% women; mean [SD] age, 48.1 [17.2] years), the weighted percentage of US adults making a recent suicide attempt increased from 0.62% in 2004-2005 (221 of 34 629) to 0.79% in 2012-2013 (305 of 34 712; ARD, 0.17%; 95% CI, 0.01%-0.33%; P = .04). In both surveys, most adults with recent suicide attempts were female (2004-2005, 60.17%; 2012-2013, 60.94%) and younger than 50 years (2004-2005, 84.75%; 2012-2013, 80.38%). The ARD for suicide attempts was significantly larger among adults aged 21 to 34 years (0.48%; 95% CI, 0.09% to 0.87%) than among adults 65 years and older (0.06%; 95% CI, -0.02% to 0.14%; interaction P = .04). The ARD for suicide attempts was also significantly larger among adults with no more than a high school education (0.49%; 95% CI, 0.18% to 0.80%) than among college graduates (0.03%; 95% CI, -0.17% to 0.23%; interaction P = .003); the ARD was also significantly larger among adults with antisocial personality disorder (2.16% [95% CI, 0.61% to 3.71%] vs 0.07% [95% CI, -0.09% to 0.23%]; interaction P = .01), a history of violent behavior (1.04% [95% CI, 0.35% to 1.73%] vs 0.00% [95% CI, -0.12% to 0.12%]; interaction P = .003), or a history of anxiety (1.43% [95% CI, 0.47% to 2.39%] vs 0.18% [95% CI, 0.04% to 0.32%]; interaction P = .01) or depressive (0.99% [95% CI, -0.09% to 2.07%] vs -0.08% [95% CI, -0.20% to 0.04%]; interaction P = .05) disorders than among adults without these conditions. Conclusions and Relevance: A recent overall increase in suicide attempts among adults in the United States has disproportionately affected younger adults with less formal education and those with antisocial personality disorder, anxiety disorders, depressive disorders, and a history of violence.

Short-term Suicide Risk After Psychiatric Hospital Discharge.

IMPORTANCE: Although psychiatric inpatients are recognized to be at increased risk for suicide immediately after hospital discharge, little is known about the extent to which their short-term suicide risk varies across groups with major psychiatric disorders. OBJECTIVE: To describe the risk for suicide during the 90 days after hospital discharge for adults with first-listed diagnoses of depressive disorder, bipolar disorder, schizophrenia, substance use disorder, and other mental disorders in relation to inpatients with diagnoses of nonmental disorders and the general population. DESIGN, SETTING, AND PARTICIPANTS: This national retrospective longitudinal cohort included inpatients aged 18 to 64 years in the Medicaid program who were discharged with a first-listed diagnosis of a mental disorder (depressive disorder, bipolar disorder, schizophrenia, substance use disorder, and other mental disorder) and a 10% random sample of inpatients with diagnoses of nonmental disorders. The cohort included 770 643 adults in the mental disorder cohort, 1 090 551 adults in the nonmental disorder cohort, and 370 deaths from suicide from January 1, 2001, to December 31, 2007. Data were analyzed from March 5, 2015, to June 6, 2016. MAIN OUTCOMES AND MEASURES: Suicide rates per 100 000 person-years were determined for each study group during the 90 days after hospital discharge and the demographically matched US general population. Adjusted hazard ratios (ARHs) of short-term suicide after hospital discharge were also estimated by Cox proportional hazards regression models. Information on suicide as a cause of death was obtained from the National Death Index. RESULTS: In the overall population of 1 861 194 adults (27% men; 73% women; mean [SD] age, 35.4 [13.1] years), suicide rates for the cohorts with depressive disorder (235.1 per 100 000 person-years), bipolar disorder (216.0 per 100 000 person-years), schizophrenia (168.3 per 100 000 person-years), substance use disorder (116.5 per 100 000 person-years), and other mental disorders (160.4 per 100 000 person-years) were substantially higher than corresponding rates for the cohort with nonmental disorders (11.6 per 100 000 person-years) or the US general population (14.2 per 100 000 person-years). Among the cohort with mental disorders, AHRs of suicide were associated with inpatient diagnosis of depressive disorder (AHR, 2.0; 95% CI, 1.4-2.8; reference cohort, substance use disorder), an outpatient diagnosis of schizophrenia (AHR, 1.6; 95% CI, 1.1-2.2), an outpatient diagnosis of bipolar disorder (AHR, 1.6; 95% CI, 1.2-2.1), and an absence of any outpatient health care in the 6 months preceding hospital admission (AHR, 1.7; 95% CI, 1.2-2.5). CONCLUSIONS AND RELEVANCE: After psychiatric hospital discharge, adults with complex psychopathologic disorders with prominent depressive features, especially patients who are not tied into a system of health care, appear to have a particularly high short-term risk for suicide.

Prevalence and correlates of anger in the community: results from a national survey.

INTRODUCTION: Little is known about the prevalence and correlates of anger in the community. METHODS: We used data derived from a large national sample of the U.S. population, which included more than 34,000 adults ages 18 years and older. We defined inappropriate, intense, or poorly controlled anger by means of self-report of the following: (1) anger that was triggered by small things or that was difficult to control, (2) frequent temper outbursts or anger that lead to loss of control, or (3) hitting people or throwing objects in anger. RESULTS: The overall prevalence of inappropriate, intense, or poorly controlled anger in the U.S. population was 7.8%. Anger was especially common among men and younger adults, and was associated with decreased psychosocial functioning. Significant and positive associations were evident between anger and parental factors, childhood, and adulthood adverse events. There were strong associations between anger and bipolar disorder, drug dependence, psychotic disorder, borderline, and schizotypal personality disorders. There was a dose-response relationship between anger and a broad range of psychopathology. CONCLUSIONS: A rationale exists for developing screening tools and early intervention strategies, especially for young adults, to identify and help reduce anger.

Testing the drug substitution switching-addictions hypothesis. A prospective study in a nationally representative sample.

IMPORTANCE: Adults who remit from a substance use disorder (SUD) are often thought to be at increased risk for developing another SUD. A greater understanding of the prevalence and risk factors for drug substitution would inform clinical monitoring and management. OBJECTIVE: To determine whether remission from an SUD increases the risk of onset of a new SUD after a 3-year follow-up compared with lack of remission from an SUD and whether sociodemographic characteristics and psychiatric disorders, including personality disorders, independently predict a new-onset SUD. DESIGN, SETTING, AND PARTICIPANTS: A prospective cohort study where data were drawn from a nationally representative sample of 34 653 adults from the National Epidemiologic Survey on Alcohol and Related Conditions. Participants were interviewed twice, 3 years apart (wave 1, 2001-2002; wave 2, 2004-2005). MAIN OUTCOMES AND MEASURES: We compared new-onset SUDs among individuals with at least 1 current SUD at wave 1 who did not remit from any SUDs at wave 2 (n = 3275) and among individuals with at least 1 current SUD at wave 1 who remitted at wave 2 (n = 2741). RESULTS: Approximately one-fifth (n = 2741) of the total sample had developed a new-onset SUD at the wave 2 assessment. Individuals who remitted from 1 SUD during this period were significantly less likely than those who did not remit to develop a new SUD (13.1% vs 27.2%, P < .001). Results were robust to sample specification. An exception was that remission from a drug use disorder increased the odds of a new SUD (odds ratio [OR] = 1.46; 95% CI, 1.11-1.92). However, after adjusting for the number of SUDs at baseline, remission from drug use disorders decreased the odds of a new-onset SUD (OR = 0.66; 95% CI, 0.46-0.95) whereas the number of baseline SUDs increased those odds (OR=1.68; 95% CI, 1.43-1.98). Being male, younger in age, never married, having an earlier age at substance use onset, and psychiatric comorbidity significantly increased the odds of a new-onset SUD during the follow-up period. CONCLUSIONS AND RELEVANCE: As compared with those who do not remit from an SUD, remitters have less than half the risk of developing a new SUD. Contrary to clinical lore, achieving remission does not typically lead to drug substitution but rather is associated with a lower risk of new SUD onsets.

Situational panic attacks in social anxiety disorder.

BACKGROUND: Panic attacks (PAs) are common in many psychiatric disorders other than panic disorder, especially social anxiety disorder (SAD). PAs have been associated with increased severity, comorbidity, and impairment in many disorders; therefore, PAs can now be used as a descriptive specifier across all DSM-5 disorders. However, the clinical implications of PAs in SAD remain unclear. METHODS: The aim of the present investigation was to examine demographic and clinical characteristics associated with SAD-related situational panic attacks in a large, representative epidemiological sample of individuals with SAD (N=1138). We compared individuals with SAD who did and did not endorse situational PAs in terms of demographic factors, fear/avoidance of social situations, distress, impairment, and diagnostic comorbidity. RESULTS: Being male, black, Asian, or over 65 years old was associated with a decreased likelihood of experiencing situational PAs, whereas being unemployed was associated with an increased likelihood. Individuals with situational PAs also exhibited greater fear and avoidance of social situations, impairment, coping-oriented substance use, treatment utilization, and concurrent and longitudinal psychiatric comorbidity. LIMITATIONS: Consistent with most epidemiologic studies, the information collected relied on self-report, and not all participants were available for both waves of assessment. CONCLUSIONS: The present findings suggest that SAD-related situational PAs are associated with more severe and complex presentations of SAD. Implications for the assessment and treatment of SAD, as well as for the use of PAs as a descriptive specifier for SAD, are discussed.

Relationship between acculturation, discrimination, and suicidal ideation and attempts among US Hispanics in the National Epidemiologic Survey of Alcohol and Related Conditions.

OBJECTIVE: Acculturation is the process by which immigrants acquire the culture of the dominant society. Little is known about the relationship between acculturation and suicidal ideation and attempts among US Hispanics. Our aim was to examine the impact of 5 acculturation measures (age at migration, time in the United States, social network composition, language, race/ethnic orientation) on suicidal ideation and attempts in the largest available nationally representative sample of US Hispanics. METHOD: Study participants were US Hispanics (N = 6,359) from Wave 2 of the 2004-2005 National Epidemiologic Survey of Alcohol and Related Conditions (N = 34,653). We used linear χ(2) tests and logistic regression models to analyze the association between acculturation and risk of suicidal ideation and attempts. RESULTS: Factors associated with a linear increase in lifetime risk for suicidal ideation and attempts were (1) younger age at migration (linear χ(2)(1) = 57.15; P < .0001), (2) longer time in the United States (linear χ(2)(1)= 36.09; P < .0001), (3) higher degree of English-language orientation (linear χ(2)(1) = 74.08; P <.0001), (4) lower Hispanic composition of social network (linear χ(2)(1) = 36.34; P < .0001), and (5) lower Hispanic racial/ethnic identification (linear χ(2)(1) = 47.77; P <.0001). Higher levels of perceived discrimination were associated with higher lifetime risk for suicidal ideation (ß = 0.051; P < .001) and attempts (ß = 0.020; P = .003). CONCLUSIONS: There was a linear association between multiple dimensions of acculturation and lifetime suicidal ideation and attempts. Discrimination was also associated with lifetime risk for suicidal ideation and attempts. Our results highlight protective aspects of the traditional Hispanic culture, such as high social support, coping strategies, and moral objections to suicide, which are modifiable factors and potential targets for public health interventions aimed at decreasing suicide risk. Culturally sensitive mental health resources need to be made more available to decrease discrimination and stigma.