METHODS Ontario respondents to the 2000–2001 Canadian Community Health Survey (CCHS) were linked with physician claim files in 2002–2003 and 2003–2004. Educational attainment and income were based on self-report. The CCHS was used for self-reported health status and Johns Hopkins Adjusted Clinical Groups was used for diagnosis-based health status.

RESULTS After adjustment, higher education was not associated with at least 1 primary care visit (odds ratio [OR] = 1.05; 95% confidence interval [CI], 0.87–1.24), but it was inversely associated with frequent visits (OR = 0.77; 95% CI, 0.65–0.88). Higher education was directly associated with at least 1 specialist visit (OR = 1.20; 95% CI, 1.07–1.34), with frequent specialist visits (OR = 1.21; 95% CI, 1.03–1.39), and with bypassing primary care to reach specialists (OR = 1.23, 95% CI 1.02–1.44). The largest inequities by education were found for dermatology and ophthalmology. Income was not independently associated with inequities in physician contact or frequency of visits.

CONCLUSIONS After adjusting for health status, we found equity in contact with primary care for educational attainment but inequity in specialist contact, frequent visits, and bypassing primary care. In this setting, universal health insurance appears to be successful in achieving income equity in physician visits. This strategy alone does not eliminate education-related gradients in specialist care.

METHODS We conducted secondary analyses of nationally representative, cross-sectional, pooled 2002–2006 data from children (n = 43,509), aged 2 to 17 years, in households responding to the Medical Expenditure Panel Survey (MEPS). We assessed 9 outcome measures pertaining to children’s unmet health care and preventive counseling needs.

RESULTS Cross-sectionally, among US children (aged 2 to 17 years) living with at least 1 parent, 73.6% were insured with insured parents, 8.0% were uninsured with uninsured parents, and the remaining 18.4% had discordant family insurance coverage patterns. In multivariable analyses, insured children with uninsured parents had higher odds of an insurance coverage gap (odds ratio [OR] = 2.45; 95% confidence interval [CI], 2.02–2.97), no usual source of care (OR = 1.31; 95% CI, 1.10–1.56), unmet health care needs (OR = 1.11; 95% CI, 1.01–1.22), and having never received at least 1 preventive counseling service (OR = 1.20; 95% CI, 1.04–1.39) when compared with insured children with insured parents. Insured children with mixed parental insurance coverage had similar vulnerabilities.

CONCLUSIONS Uninsured children had the highest rates of unmet needs overall, with fewer differences based on parental insurance status. For insured children, having uninsured parents was associated with higher odds of going without necessary services when compared with having insured parents.

METHODS We conducted a prospective cohort study of primary care patients with type 2 diabetes at Group Health Cooperative in Washington state. We used the Patient Health Questionnaire (PHQ-9) to assess depression at baseline and reviewed medical records supplemented by the Washington state mortality registry to ascertain the causes of death.

RESULTS Among a cohort of 4,184 patients, 581 patients died during the follow-up period. Deaths occurred among 428 (12.9%) patients with no depression, among 88 (17.8%) patients with major depression, and among 65 (18.2%) patients with minor depression. Causes of death were grouped as cardiovascular disease, 42.7%; cancer, 26.9%; and deaths that were not due to cardiovascular disease or cancer, 30.5%. Infections, dementia, renal failure, and chronic obstructive pulmonary disease were the most frequent causes in the latter group. Adjusting for demographic characteristics, baseline major depression (relative to no depression) was significantly associated with all-cause mortality (hazard ratio [HR]=2.26, 95% confidence interval [CI], 1.79–2.85), with cardiovascular mortality (HR = 2.00; 95% CI, 1.37–2.94), and with noncardiovascular, noncancer mortality (HR = 3.35; 95% CI, 2.30–4.89). After additional adjustment for baseline clinical characteristics and health habits, major depression was significantly associated only with all-cause mortality (HR = 1.52; 95% CI, 1.19–1.95) and with death not caused by cancer or atherosclerotic cardiovascular disease (HR = 2.15; 95% CI, 1.43–3.24). Minor depression showed similar but nonsignificant associations.

CONCLUSIONS Patients with diabetes and coexisting depression face substantially elevated mortality risks beyond cardiovascular deaths.

METHODS In 11 family practices (total practice population = 49,229) in The Netherlands, we conducted a stepwise opportunistic screening program among patients aged 45 to 75 years by (1) identifying high-risk individuals (=1 diabetes risk factor) and low-risk individuals using the electronic medical record, (2) obtaining a capillary fasting plasma glucose measurement, repeated on a separate day if the value was greater than 110 mg/dL, and (3) obtaining a venous sample if both capillary fasting plasma glucose values were greater than 110 mg/dL and at least 1 sample was 126 mg/dL or greater. We calculated the yield (percentage of invited patients with undiagnosed diabetes), number needed to screen (NNS), and diagnostic value of the risk factors (odds ratio and area under the receiver operating characteristic curve).

RESULTS We invited for a first capillary measurement 3,724 high-risk patients seen during usual care and a random sample of 465 low-risk patients contacted by mail. The response rate was 90% and 86%, respectively. Ultimately, 101 high-risk patients (2.7%; 95% confidence interval [CI], 2.2%–3.3%; NNS = 37) and 2 low-risk patients (0.4%; 95% CI, 0.1%–1.6%; NNS = 233) had undiagnosed diabetes (P <.01). The prevalence of diabetes among patients 45 to 75 years old increased from 6.1% to 6.8% as a result. Among diagnostic models containing various risk factors, a model containing obesity alone was the best predictor of undiagnosed diabetes (odds ratio = 3.2; 95% CI, 2.0–5.2; area under the curve=0.63).

CONCLUSIONS The yield of opportunistic targeted screening was fair; obesity alone was the best predictor of undiagnosed diabetes. Opportunistic screening for type 2 diabetes in primary care could target middle-aged and older adults with obesity.

METHODS We conducted an Internet search using 2 major search engines (Google and Yahoo) with the key words "purchase antibiotics without a prescription" and "online (English only)." Vendors were compared according to the classes of antibiotics available, quantity, shipping locations, and shipping time.

RESULTS We found 138 unique vendors selling antibiotics without a prescription. Of those vendors, 36.2% sold antibiotics without a prescription, and 63.8% provided an online prescription. Penicillins were available on 94.2% of the sites, macrolides on 96.4%, fluoroquinolones on 61.6%, and cephalosporins on 56.5%. Nearly all, 98.6%, ship to the United States. The mean delivery time was 8 days, with 46.1% expecting delivery in more than 7 days. Among those selling macrolides (n = 133), 93.3% would sell azithromycin in quantities consistent with more than a single course of medication. Compared with vendors that require a medical interview, vendors who sell antibiotics without a prescription were more likely to sell quantities in excess of a single course, and the antibiotics were more likely to take more than 7 days to reach the customer.

CONCLUSIONS Antibiotics are freely available for purchase on the Internet without a prescription, a phenomenon that encourages self-medication and low quality of care.

METHODS We conducted a randomized trial to determine the effectiveness of a computer-assisted motivational intervention (CAMI) in preventing rapid subsequent birth to adolescent mothers. Pregnant teenagers (N = 235), aged 18 years and older who were at more than 24 weeks’ gestation, were recruited from urban prenatal clinics serving low-income, predominantly African American communities. After completing baseline assessments, they were randomly assigned to 3 groups: (1) those in CAMI plus enhanced home visit (n = 80) received a multi-component home-based intervention (CAMI+); (2) those in CAMI–only (n = 87) received a single component home-based intervention; (3) and those in usual-care control (n = 68) received standard usual care. Teens in both intervention groups received CAMI sessions at quarterly intervals until 2 years’ postpartum. Those in the CAMI+ group also received monthly home visits with parenting education and support. CAMI algorithms, based on the transtheoretical model, assessed sexual relationships and contraception-use intentions and behaviors, and readiness to engage in pregnancy prevention. Trained interventionists used CAMI risk summaries to guide motivational interviewing. Repeat birth by 24 months’ postpartum was measured with birth certificates.

RESULTS Intent-to-treat analysis indicated that the CAMI+ group compared with the usual-care control group exhibited a trend toward lower birth rates (13.8% vs 25.0%; P = .08), whereas the CAMI-only group did not (17.2% vs 25.0%; P = .32). Controlling for baseline group differences, the hazard ratio (HR) for repeat birth was significantly lower for the CAMI+ group than it was with the usual-care group (HR = 0.45; 95% CI, 0.21–0.98). We developed complier average causal effects models to produce unbiased estimates of intervention effects accounting for variable participation. Completing 2 or more CAMI sessions significantly reduced the risk of repeat birth in both groups: CAMI+ (HR = 0.40; 95% CI, 0.16–0.98) and CAMI–only (HR = 0.19; 95% CI, 0.05–0.69).

CONCLUSIONS Receipt of 2 or more CAMI sessions, either alone or within a multicomponent home-based intervention, reduced the risk of rapid subsequent birth to adolescent mothers.

METHODS We undertook an observational cohort study set in 21 Dutch general practices, including 682 patients with nontraumatic complaints of arm, neck, and shoulder. The outcome measure was application (yes/no) of a specific management option: watchful waiting, additional diagnostic tests, prescription of medication, corticosteroid injection, referral for physiotherapy, and referral for medical specialist care.

RESULTS Separate multilevel analyses showed that overall, the diagnostic category, having long duration of complaints, and reporting many functional limitations were most frequently associated with the choice of a management option. For watchful waiting, only complaint variables played a role (long duration of complaints, high complaint severity, many functional limitations, recurrent complaint). All these variables were negatively associated with watchful waiting. When opting for 1 of the 5 other management options, several physician characteristics played a role as well. Less clinical experience was associated with additional diagnostic tests and referral to a medical specialist. GPs working in a solo practice more frequently referred to a medical specialist. GPs working in a rural area more frequently referred for physiotherapy. Female GPs prescribed medication less frequently. Physicians with special interest in musculoskeletal complaints gave corticosteroid injections more frequently.

CONCLUSIONS Diagnostic category, long duration of complaints, and high functional limitations were key variables in management decisions with these complaints. In addition, several physician characteristics played a role as well.

METHODS We searched PubMed, PsycINFO, CINAHL, EMBASE, and Cochrane Libraries from inception to May 28, 2008, for studies examining the diagnostic accuracy of Spanish language depression case-finding instrument(s) administered to primary-care outpatients. Two authors independently assessed studies for inclusion and quality.

RESULTS Twelve studies met inclusion criteria. In general primary care screening, the Spanish language version of the Center for Epidemiologic Studies-Depression scale (CES-D) had sensitivities ranging from 76% to 92% and specificities ranging from 70% to 74%. We found no US study reporting the accuracy of the Primary Care Evaluation of Mental Disorders (PRIME-MD-9) or the Patient Health Questionnaire (PHQ-9) depression module in Spanish-speakers. One fair-quality European study and 1 poor-quality study conducted in Honduras found the 9-item PRIME-MD had sensitivities ranging from 72% to 77% and specificities ranging from 86% to 100%. The 2-item PRIME-MD was 92% sensitive, but only 44% specific for depression in 1 US study. In geriatric outpatients, the 15-item Spanish language version of the Geriatric Depression Scale (GDS) had sensitivities ranging from 76% to 82%, and specificities ranging from 64% to 98%. In postpartum women, the Spanish language version of the Edinburgh Postnatal Depression Scale (EPDS) was 72% to 89% sensitive and 86% to 95% specific for major depression (2 non-US studies). The Spanish language version of the Postpartum Depression Screening Scale (PDSS) was 78% sensitive and 85% specific for combined major/minor depression (1 US study).

CONCLUSIONS For depression screening in Spanish-speaking outpatients, fair evidence supports the diagnostic accuracy of the CES-D and PRIME-MD-9 in general primary care, the GDS-15-Spanish for geriatric patients, and the Spanish language versions of the EPDS or PDSS for postpartum patients. The ultrashort 2-item version of PRIME-MD may lack specificity in US Spanish-speakers.