Search Results

Methods: Using the National Longitudinal Survey of Youth--Cohort 1997, multivariate logistic regression models were fit to estimate the association between chronic health conditions and educational attainment, adjusting for confounders. Chronic health conditions were defined as a parental (1997) or participant (2002) report of a chronic health condition and classified into (1) asthma; (2) cancer, diabetes, and epilepsy; (3) heart conditions; and (4) other. Educational attainment was defined as receiving a high school diploma or Graduate Equivalency Degree by age 21, determined from self-report.

Results: Youth who reported having a chronic health condition had higher odds of low educational attainment compared with youth who did not report a condition (n = 6,795; odds ratio [OR], 1.47; 95% confidence interval [CI], 1.22-1.76). Specifically, youth with asthma (OR, 1.63; 95% CI, 1.31-2.02) and those with cancer, diabetes, or epilepsy (OR, 1.96; 95% CI, 1.13-3.37) had higher odds of low attainment. For youth who reported cancer, diabetes, or epilepsy, the variables "school absences," "repeated a grade," and "depressive symptoms" attenuated the association and were considered mediators.

Conclusions: Youth with chronic health conditions had lower educational attainment. Students with cancer, diabetes, or epilepsy who had a high number of absences, had repeated a grade, or had a high-depressive symptoms score were particularly impacted.

Methods
Drawing from a nationally representative longitudinal survey of adolescents (NLSY97; N = 4980), this study used ordinary least squares (OLS) regression models, lagged regression models, and family fixed-effects models to assess whether parental knowledge, parent negativity, and family activities during midadolescence predicted differences in late adolescent sexual risk behaviors.

Results
Even after controlling for unobserved heterogeneity across individuals and across families, parenting processes significantly predicted later adolescent sexual risk behaviors. Specifically, more regular family activities and less negative and hostile parenting during mid-adolescence predicted lower sexual risk behaviors during late adolescence.

Conclusions
Results concerning the buffering effects of parenting on adolescent risk behaviors help to inform prevention and intervention efforts. Through the use of more rigorous statistical methodology and large representative samples of youth, this research provides an exemplar of how survey research can seek to move closer to understanding causal processes in the exceedingly complex systems of human development.

Methods: Using panel data from the National Longitudinal Survey of Youth 1997, we estimated longitudinal trajectories of handgun carrying among urban Americans, who carried a handgun at least once between 1997 and 2011 (N = 1,574). Multinomial logistic regression analyses examined risk factors associated with handgun-carrying trajectory groups during late adolescence (ages 16-20), emerging adulthood (ages 20-24), and young established adulthood (ages 24-28).

Methods: We linked person-level gun carrying data from a nationally representative sample of U.S. youth and young adults with state-level gun policies over a 15-year period. Cross-classified mixed effects logistic regressions estimated the associations between state gun policies and handgun carrying and explored whether the associations varied by person-level demographic characteristics.

Results: Youth and young adults in states with a greater number of gun policies were less likely to carry a handgun than youth and young adults in states with fewer gun policies. Regulations on gun purchasing, concealed carrying permitting, and domestic violence-related laws were particularly important in reducing youth/young adult gun-carrying behavior. In addition, these associations varied by gender and race/ethnicity.

Discussion: State firearm legislation may be an effective mechanism to reduce youth and young adult gun carrying and ultimately mitigate gun-related mortality and morbidity.

Methods: Data were drawn from 4,079 male and 4,059 female participants of the National Longitudinal Study of Youth 1997, aged 12-16 years at the first assessment. Cox proportional hazards regression models were estimated predicting age at first sexual intercourse from age at first alcohol use, without and with adjustment for correlated sociodemographic and individual- and family-level risk factors. Analyses were conducted separately for males and females, with interactions between alcohol use and respondent sex (female vs. male) modeled in subsidiary analyses.

Results: Onset of first drink was strongly predictive of earlier sexual intercourse for both males and females, with effects of drinking most pronounced for females during early adolescence.

Methods: Data from two separate studies were used: a national sample of 3,436 14–18-year-old adolescents and a regional sample of 124 seventh graders and 132 ninth graders, 12–16 years old. Participants were asked about their chance of dying in the next year and before age 20, and about the extent of various threats to their physical well-being.

Results: Adolescents in both samples greatly overestimated their chance of dying. Those mortality estimates were higher for adolescents who reported direct threats (e.g., an unsafe neighborhood). Thus, adolescents were sensitive to the relative size of threats to their survival, but not to the implications for absolute risk levels.

Conclusions: Contrary to the folk wisdom that adolescents have a unique sense of invulnerability, the individuals studied here reported an exaggerated sense of mortality, which was highest among those reporting greater threats in their lives. Such fears could affect adolescents' short-term well-being and future planning. Copyright 2009 Society for Adolescent Medicine. All rights reserved.

Methods: Longitudinal and cross-sectional data were obtained from four nationally representative surveys: National Health and Nutrition Examination Survey, National Longitudinal Study of Adolescent Health, National Health Interview Survey, and National Longitudinal Surveys of Youth (NLSY79 and NLSY97). The analysis tracked age trends in BMI by time, which allowed for the examination of how BMI changed during the transition to adulthood and whether the patterns of change varied by period. Data best suited for trend analysis were identified. Age trends in BMI by gender and race were graphed and regression analysis was used to test for significant differences in the trends using the National Health and Nutrition Examination Survey and National Longitudinal Study of Adolescent Health.

Results: BMI increased sharply in the adolescent ages, beginning in the 1990s and among young adults around 2000. This age pattern of BMI increase was more dramatic among females and blacks, particularly black females.

Conclusions: BMI increased during the transition to adulthood and these increases have grown larger over time. Obesity prevention efforts should focus on this high-risk transition period, particularly among minority populations.

Methods: We used the American National Longitudinal Survey of Youth 1979 Child/Young Adult (n = 6,315) and the Canadian National Longitudinal Survey of Children and Youth (n = 3,666). Depressive symptoms were measured using five items from the Center for Epidemiological Studies on Depression scale. Latent trajectories of depressive symptoms from ages 16-25 years were identified using growth mixture models. We estimated the effect of childhood family income, parental education, and parental unemployment on trajectory membership using multivariable Poisson regression models with robust variances.

Results: We identified four similar trajectories in the two countries: (1) low stable; (2) mid-peak; (3) increasing; and (4) decreasing. Relatively more Americans were in the low-stable trajectory group than Canadians (77.6% vs. 64.9%), and fewer Americans were in the decreasing group (7.1% vs. 19.1%). In the U.S., childhood family income in the bottom two quartiles was related to higher rates of increasing trajectory membership compared with income in the top quartile (incidence rate ratios: 1.59–1.79, p < .05), but not in Canada. In the U.S., parental education at a high school level was associated with higher rates of decreasing trajectory membership compared with higher education (incidence rate ratio = 1.45, confidence interval: 1.10–1.91; p = .01), but not in Canada.

Methods: Data were from the National Longitudinal Survey of Youth 1997, which is representative of youth born between 1980 and 1984. Age-specific patterns of gang joining, participation, and leaving are estimated based on youths (N=7,335) self-reported gang membership at the baseline and eight subsequent interviews, which were combined with population age estimates from the 2010 U.S. Census to produce national estimates of gang membership. Sampling variance-adjusted bounds were estimated based on assumptions about missing cases and survey design effects. Demographic and socioeconomic variables are used to compare differences between gang and nongang youth.

Results: Youth gang members were disproportionately male, black, Hispanic, from single-parent households, and families living below the poverty level. We estimated that there were 1,059,000 youth gang members in the United States in 2010 (bounds ranging from 675,000 to 1,535,000). The prevalence of youth gang membership was 2.0% (1.2%-2.8%), peaking at age 14 years at 5.0% (3.9%-6.0%). Annually, 401,000 (204,000-639,000) juveniles join gangs and 378,000 (199,000-599,000) exit gangs, with a turnover rate of 36%.

Conclusions: We discovered that significantly more people are involved with gangs than previous estimates would suggest. Clinicians and policy makers must recognize that youth gang members may not conform to popular perceptions of gang demographics. The patterns of youth gang membership observed in this study support prevention programs aimed at children before the teen years. This strategy is more likely to succeed than gang intervention or suppression strategies aimed at teens.

Methods: We analyzed nationally representative data from 1997 through 2019 (N = 8,961) using the National Longitudinal Survey of Youth 1997. An ordinary least squares regression model using inverse probability weights was used to assess the influence of youth incarceration in an adult facility on average mental health scores from age 18 to 37.

Results: Respondents incarcerated in an adult facility as a youth had poorer average mental health than those not held in adult prisons or jails over the course of the study period. Those incarcerated for longer in adult facilities also exhibited more mental health symptoms.

Discussion: Young people incarcerated in adult correctional facilities experience poorer long-term mental health related to depression and anxiety in early adulthood.

Methods: In 2018, a prospective analysis was conducted using data from 5,040 adolescents aged 9-24 and their mothers who completed the two-generation National Longitudinal Survey of Youth in 2006 (first interview) and 2008 (second interview). Findings include percentages and adjusted odds ratios of the factors that predict adolescents' self-report of routine care use in the past year measured at the second interview.

Results: In 2008, over half of participants reported a routine doctor visit during the prior 12 months and this varied by gender; more females (68.7%) had a visit than males (53.5%). Factors that independently predicted a greater odds of adolescents' routine doctor visits included mothers with routine doctor visits at both interviews or the second interview only, and adolescents' health insurance and past routine visit, regardless of gender. Males aged 18-20 and 21-24 years had lower odds of having a routine doctor visit than males aged 9-11 years.

Methods: Using nationally representative data from the 1997 cohort of the National Longitudinal Survey of Youth, we exploited state-specific first-grade entrance policy as a quasi-experimental research design to examine the effect of early school entry on the body weight status of adolescent girls. Fixed-effects models were used to compare the body mass index (BMI), BMI z-score, and likelihood of overweight and obesity between teenage girls born before school cut-off dates and those born after, while controlling for age, race/ethnicity, maternal education status, and maternal body weight status

Results: Late starters had higher BMIs and a higher prevalence of overweight and obesity and the results were found to be consistent across age groups. Among girls whose birthdays were within 1 month of the cut-off dates, the coefficient of late starting was significantly positive (Beta=.311; p=.02), indicating that it might be correlated with weight gain in adolescence.

Conclusions: Early admission to a school environment might have a long-term protective effect in terms of adolescent girls’ propensity to obesity. Future studies are needed to examine the effect of early school entry on the eating behavior and physical activities of adolescent girls.