BACKGROUND: Only half of US schoolchildren receive influenza vaccine. School-located influenza vaccination (SLIV) might raise vaccination rates but conducting flu vaccine clinics at schools is challenging to implement. We compared 2 school-based programs designed to raise influenza vaccination rates: parent reminder/educational messages sent to parents from schools which is a low-intensity intervention vs the combination of reminder/educational messages plus SLIV clinics which is a high-intensity intervention. METHODS: We assigned 36 schools (6 school districts, 2 per group) to 3 groups: (1) control, ie, no SLIV and no parent reminder/education, (2) parent reminder/education emailed by schools, and (3) parent reminder/education plus SLIV clinics. Some schools had SLIV clinics in prior years. Health department nurses conducted SLIV clinics. RESULTS: Among 24,832 children at 36 schools, vaccination rates were control (51.3%), parent reminder/education-only (41.2%), and reminder/education + SLIV (58.7%). On multivariate analyses which controlled for vaccination in prior seasons, children in reminder/education + SLIV schools had higher vaccination rates (OR 1.27, 95% CI 1.10-1.47), but children in reminder/education-only schools had lower rates (OR 0.87, 95% CI 0.75-1.00) than children in control schools. CONCLUSIONS: Parent reminder/education combined with SLIV clinics raise vaccination rates, but parent reminder/education alone does not.

BACKGROUND: Higher income population tend to prefer brand-name to generic drugs, which may cause disparity in access to brand-name drugs among income groups. A potential policy that can resolve such disparity is imposing a greater co-payment rate on high-income enrollees. However, the effects of such policy are unknown. We examined how patients' choice between brand-name and generic drugs are affected by the unique income-based co-payment rates in Japan; 10% for general enrollees and 30% for those with high income among the elderly aged 75 and over. METHODS: We drew on cross-sectional price variation among commonly prescribed 311 drugs using health insurance claims data from a large prefecture in Japan between October 2013 and September 2014 to identify between-income-group differences in responses to differentiated payments. RESULTS: Running 311 multivariate logistic regression models controlling individual demographics, the median estimate indicated that high-income group was 3% (odds ratio = 0.97) less likely to choose a generic drug than the general-income group and the interquartile estimates ranged 0.92-1.02. The multivariate feasible generalized least squares model indicated high-income group's higher likelihood to choose brand-name drugs than the general-income group without co-payment rate differentiation (p < 0.001). Such gap in the likelihood was attenuated by 0.4% (p = 0.027) with an US$1 increase in the difference in additional payment/month for brand-name drugs between income groups - no gap with US$10 additional payment/month. This attenuation was observed in drugs for chronic diseases only, not for acute diseases. CONCLUSIONS: Income-based co-payment rates appeared to reduce disparity in access to brand-name drugs across income groups, in addition to reducing total medical expenditure among high-income group who shifted from brand-name drugs to generic ones due to larger drug price differences.

BACKGROUND: Studies have noted variations in the cost-effectiveness of school-located influenza vaccination (SLIV), but little is known about how SLIV's cost-effectiveness may vary by targeted age group (e.g., elementary or secondary school students), or vaccine consent process (paper-based or web-based). Further, SLIV's cost-effectiveness may be impacted by its spillover effect on practice-based vaccination; prior studies have not addressed this issue. METHODS: We performed a cost-effectiveness analysis on two SLIV programs in upstate New York in 2015-2016: (a) elementary school SLIV using a stepped wedge design with schools as clusters (24 suburban and 18 urban schools) and (b) secondary school SLIV using a cluster randomized trial (16 suburban and 4 urban schools). The cost-per-additionally-vaccinated child (i.e., incremental cost-effectiveness ratio (ICER)) was estimated by dividing the incremental SLIV intervention cost by the incremental effectiveness (i.e., the additional number of vaccinated students in intervention schools compared to control schools). We performed deterministic analyses, one-way sensitivity analyses, and probabilistic analyses. RESULTS: The overall effectiveness measure (proportion of children vaccinated) was 5.7 and 5.5 percentage points higher, respectively, in intervention elementary (52.8%) and secondary schools (48.2%) than grade-matched control schools. SLIV programs vaccinated a small proportion of children in intervention elementary (5.2%) and secondary schools (2.5%). In elementary and secondary schools, the ICER excluding vaccine purchase was $85.71 and $86.51 per-additionally-vaccinated-child, respectively. When additionally accounting for observed spillover impact on practice-based vaccination, the ICER decreased to $80.53 in elementary schools -- decreasing substantially in secondary schools. (to $53.40). These estimates were higher than the published practice-based vaccination cost (median = $25.50, mean = $45.48). Also, these estimates were higher than our 2009-2011 urban SLIV program mean costs ($65) due to additional costs for use of a new web-based consent system ($12.97 per-additionally-vaccinated-child) and higher project coordination costs in 2015-2016. One-way sensitivity analyses showed that ICER estimates were most sensitive to the SLIV effectiveness. CONCLUSIONS: SLIV raises vaccination rates and may increase practice-based vaccination in primary care practices. While these SLIV programs are effective, to be as cost-effective as practice-based vaccination our SLIV programs would need to vaccinate more students and/or lower the costs for consent systems and project coordination. TRIAL REGISTRATION: ClinicalTrials.gov NCT02227186 (August 25, 2014), updated NCT03137667 (May 2, 2017).

Half of US school children receive influenza vaccine. In our previous trials, school-located influenza vaccination (SLIV) raised vaccination rates by 5 to 8 percentage points. We assessed whether text message reminders to parents could raise vaccination rates above those observed with SLIV. Within urban elementary schools we randomized families into text message + SLIV (intervention) versus SLIV alone (comparison). All parents were sent 2 backpack notifications plus 2 autodialer phone reminders about SLIV at a single SLIV clinic. Intervention group parents also were sent 3 text messages from the school nurse encouraging flu vaccination via either primary care or SLIV. Among 15 768 children at 32 schools, vaccination rates were text + SLIV (40%) and SLIV control (40%); 4% of students per group received influenza vaccination at SLIV. Text message reminders did not raise influenza vaccination rates above those observed with SLIV alone. More intensive interventions are needed to raise influenza vaccination rates.

BACKGROUND: Influenza vaccination rates among children are low and novel strategies are needed to raise coverage. We measured the impact of school-located influenza vaccination (SLIV) on coverage, examined whether SLIV substitutes for practice-based influenza vaccination ("substitution"), and estimated whether a second year of experience with SLIV increases its impact. METHODS: We implemented a stepped wedge study design with schools as clusters. In Year 1, we randomly allocated schools to SLIV or control. In Year 2, all schools performed SLIV. We used emails (suburban schools) or backpack fliers (both urban and suburban schools) to notify parents, and offered web-based (suburban) or paper-based vaccination (urban) consent forms. Local health department nurses administered SLIV vaccinations and billed insurers. We analyzed state immunization registry data to measure influenza vaccination rates. RESULTS: 42 schools (38,078 children) participated over 2 years. Overall vaccination rates were 5 and 7 percentage points higher among SLIV- school children versus control-school children in suburban (aOR 1.36, 95% CI 1.25-1.49 in Years 1-2 SLIV vs. Year 1 control schools) and urban schools (aOR 1.22, 95% CI 1.10-1.36), respectively, adjusting for prior year's vaccination and other covariates. While no substitution occurred among children attending suburban schools, some substitution occurred among children attending urban schools, although overall vaccination rates were still higher in urban schools due to SLIV. Compared to an initial year of SLIV, more children were vaccinated in a second year of SLIV at urban (8.3% vs. 6.8%, aOR 1.24, 95% CI 1.04-1.47) but not suburban schools (3.5% vs. 2.7%, aOR 1.24, 95% CI 0.98-1.57). CONCLUSIONS: In this stepped wedge trial, SLIV increased overall influenza vaccination rates in suburban and urban schools. Some substitution for primary care vaccination occurred in urban settings. A second year of SLIV expanded its reach slightly in urban schools.

BACKGROUND: Direct-to-consumer information (DTCI) campaign is a new medium to inform and empower patients in their decision-making without directly promoting specific drugs. However, little is known about the impact of DTCI campaigns, expanding rapidly in developed countries, on changes in prescription patterns. We sought to determine whether a DTCI campaign on overactive bladder increases the prescription rate for overactive bladder treatment drugs. METHODS: We performed a 3-year retrospective cohort study of 1332 participants who were diagnosed overactive bladder but not prescribed treatment drugs prior to the examined DTCI campaign (exposure), using the health insurance claims dataset of the Japan Medical Data Center (November 19, 2010 to November 18, 2013). The DTCI campaign for overactive bladder included television, Internet, and print advertising (November 19, 2011 to December 22, 2011). We divided the study period into Pre-Campaign Year (2010-2011), Year 1 (2011-2012), and Year 2 (2012-2013). Each year began on November 19 and included Period 1 (weeks 1-5) through Period 10 (weeks 46-50). The main outcome was first-time prescription of the treatment drug for each patient, measured by 5-week periods. Using Period 10 in the Pre-Campaign Year as the referent period, we applied the Cox proportional hazard model for each period. Additionally, we performed the interrupted time series analysis (ITSA) for the first-time prescription rate per 5-week period. RESULTS: Following the DTCI campaign, patients were about seven times more likely to receive a first prescription of a treatment drug during Period 4 in Year 1 (hazard ratio 7.09; 95% CI, 2.11-23.8; p-value<.01) compared with the reference period. Similar increases were also observed for subsequent Periods 5 and 6 in Year 1. The ITSA confirmed the DTCI campaign impact on the level of prescription rate (one-time increase in the regression-intercept) that increased by 1128.1 [per standardized 100,000 persons] (p < .05) during Period 4 in Year 1. CONCLUSIONS: The examined DTCI campaign appeared to increase the prescription rate among patients with overactive bladder for 15 weeks with a 15-week delay. Clinical outcomes of the patients with targeted diseases need to be monitored after DTCI campaigns by a future study.

PURPOSE: We aimed to evaluate the effect of school-located influenza vaccination (SLIV) on adolescents' influenza vaccination rates. METHODS: In 2015-2016, we performed a cluster-randomized trial of adolescent SLIV in middle/high schools. We selected 10 pairs of schools (identical grades within pairs) and randomly allocated schools within pairs to SLIV or usual care control. At eight suburban SLIV schools, we sent parents e-mail notifications about upcoming SLIV clinics and promoted online immunization consent. At two urban SLIV schools, we sent parents (via student backpack fliers) paper immunization consent forms and information about SLIV. E-mails were unavailable at these schools. Local health department nurses administered nasal or injectable influenza vaccine at dedicated SLIV clinics and billed insurers. We compared influenza vaccination rates at SLIV versus control schools using school directories to identify the student sample in each school. We used the state immunization registry to determine receipt of influenza vaccination. RESULTS: The final sample comprised 17,650 students enrolled in the 20 schools. Adolescents at suburban SLIV schools had higher overall influenza vaccination rates than did adolescents at control schools (51% vs. 46%, p < .001; adjusted odds ratio = 1.27, 95% confidence interval 1.18-1.38, controlling for vaccination during the prior two seasons). No effect of SLIV was noted among urbanschools on multivariate analysis. SLIV did not substitute for vaccinations in primary care or other settings; in suburban settings, SLIV was associated with increased vaccinations in primary care or other settings (adjusted odds ratio = 1.10, 95% confidence interval 1.02-1.19). CONCLUSIONS: SLIV in this community increased influenza vaccination rates among adolescents attending suburban schools.

BACKGROUND: Telemedicine in the intensive care unit (tele-ICU) is expected to address geographic health disparities through more efficient resource allocation. Our previous economic evaluation demonstrated tele-ICU to be cost-effective in most cases and cost saving in some cases, compared to conventional intensive care unit (ICU) care without adequate intensivist coverage. INTRODUCTION: This study's objective is to examine how to optimize the cost-effectiveness of tele-ICU use by selecting highest risk (i.e., both highest mortality and highest cost) subpopulations. We also explore potential cost savings. MATERIALS AND METHODS: We conducted simulation analyses among a hypothetical adult ICU patient cohort defined by the literature, distinguishing four types of hospitals: urban tertiary (primary analysis), urban community, rural tertiary, and rural community. The selected tele-ICU use was assumed to affect per-patient ICU cost and hospital mortality among highest risk subpopulations (10-100% of all ICU patients), defined by an established illness-severity measure. RESULTS: We found a U-shaped relationship between the economic efficiency and selected tele-ICU use among all 4 hospital types. Optimal cost-effectiveness was achieved when tele-ICU was applied to the 30-40% highest risk patients among all ICU patients (incremental cost-effectiveness ratio = $25,392 [2014 U.S. dollars] per extending a quality-adjusted life year) in urban tertiary hospitals (primary analysis). Our break-even analyses indicated that cost saving seems more feasible when reducing ICU medical care cost, rather than lowering the cost to operate telemedicine alone. DISCUSSION AND CONCLUSIONS: A selected use of tele-ICU based on severity of illness is likely to improve tele-ICU cost-effectiveness. To achieve cost saving, tele-ICU must reduce more than just telemedicine-related cost.

Reversing the obesity epidemic has been a persistent global public health challenge, particularly among low socioeconomic status populations and racial/ethnic minorities. We developed a novel concept of community-based incentives to approach this problem in such communities. Applying this concept, we proposed a school intervention to promote obesity prevention in the U.S. We conducted a pilot survey to explore attitudes towards this future intervention. The survey was collected as a nonprobability sample (N = 137 school-aged children (5-12 years)) in northern California in July 2013. We implemented multivariable logistic regression analyses where the dependent variable indicated the intention to participate in the future intervention. The covariates included the body mass index (BMI) based weight categories, demographics, and others. We found that the future intervention is expected to motivate generally-high-risk populations (such as children and parents who have never joined a past health-improvement program compared to those who have completed a past health-improvement program (the odds-ratio (OR) = 5.84, p < 0.05) and children with an obese/overweight parent (OR = 2.72, p < 0.05 compared to those without one)) to participate in future obesity-prevention activities. Our analyses also showed that some subgroups of high-risk populations, such as Hispanic children (OR = 0.27, p < 0.05) and children eligible for a free or reduced price meal program (OR = 0.37, p < 0.06), remain difficult to reach and need an intensive outreach activity for the future intervention. The survey indicated high interest in the future school intervention among high-risk parents who have never joined a past health-improvement program or are obese/overweight. These findings will help design and implement a future intervention.

The severe economic recession from December 2007 to December 2010 substantially affected registered nurse (RN) employment. The objective of this study was to determine if the association between RN workforce supply and its potential determinants differed during the period from 2008 to 2012. Older, experienced RNs were more likely to work in 2010, compared to 2008, but less likely to work in 2012 compared to 2010. RNs were less sensitive to financial factors in 2010 than in 2008, but were more sensitive in 2012 than in 2010. These recession-driven changes in employment may have had impacts on the labor market for newly graduating RNs.

OBJECTIVE: Assess impact of offering school-located influenza vaccination (SLIV) clinics using both Web-based and paper consent upon overall influenza vaccination rates among elementary school children. METHODS: We conducted a cluster-randomized trial (stratified by suburban/urban districts) in upstate New York in 2014-2015. We randomized 44 elementary schools, selected similar pairs of schools within districts, and allocated schools to SLIV versus usual care (control). Parents of children at SLIV schools were sent information and vaccination consent forms via e-mail, backpack fliers, or both (depending on school preferences) regarding school vaccine clinics. Health department nurses conducted vaccine clinics and billed insurers. For all children registered at SLIV/control schools, we compared receipt of influenza vaccination anywhere (primary outcome). RESULTS: The 44 schools served 19 776 eligible children in 2014-2015. Children in SLIV schools had higher influenza vaccination rates than children in control schools county-wide (54.1% vs 47.4%, P < .001) and in suburban (61.9% vs 53.6%, P < .001) and urban schools (43.9% vs 39.2%; P < .001). Multivariate analyses (controlling for age, grade, vaccination in previous season) confirmed bivariate findings. Among parents who consented for SLIV, nearly half of those notified by backpack fliers and four-fifths of those notified by e-mail consented online. In suburban districts, SLIV did not substitute for primary care influenza vaccination. In urban schools, some substitution occurred. CONCLUSIONS: SLIV raised seasonal influenza vaccination rates county-wide and in both suburban and urban settings. SLIV did not substitute for primary care vaccinations in suburban settings where pediatricians often preorder influenza vaccine but did substitute somewhat in urban settings.

BACKGROUND: The proportion of registered nurses (RNs) with employment in health-related positions before their initial RN education has increased in the past two decades. Previous research found that prior health-related employment is positively associated with RN workforce supply, potentially due to the wage differences based on different career paths. This study's objective is to test the hypotheses that prior health-related employment is associated with differences in starting wages and with different rates of wage growth for experience as an RN. METHODS: We conducted a cross-sectional analysis using the 2008 National Sample Survey of Registered Nurses (NSSRN) linked with county-level variables from the Area Health Resource File. We estimated a Heckman model where the second-stage equation's outcome variable was the logarithm of the RN hourly wage, accounting for the self-selection of working or not working as an RN (i.e., the first-stage equation's outcome variable). Key covariates included interaction terms between years of experience, experience squared, and six categories of prior health-related employment (manager, LPN/LVN, allied health, nursing aide, clerk, and all other healthcare positions). Additional covariates included demographics, weekly working hours, marital status, highest nursing degree, and county-level variables (e.g., unemployment rate). We estimated the marginal effect of experience on wage for each type of prior health-related employment, conducting separate analyses for RNs whose initial education was a Bachelor of Science in Nursing (BSN) (unweighted N = 10,345/weighted N = 945,429), RNs whose initial education was an Associate degree (unweighted N = 13,791/weighted N = 1,296,809), and total population combining the former groups (unweighted N = 24,136/weighted N = 2,242,238). RESULTS: Prior health-related employment was associated with higher wages, with the strongest wage differences among BSN-educated RNs. Among BSN-educated RNs, previous employment as a health care manager, LPN/LVN, or nursing aide produced statistically higher starting wages ($1.72-$3.86 per hour; $3400-$7700 per year; p = 0.006-0.08). However, experience-based wage growth was lower for BSN-educated RNs previously employed as allied health workers, LPN/LVNs, or nursing aides. Among Associate degree-educated RNs, wage difference was not observed except for higher initial wage for RNs with previous employment as LPN/LVNs. CONCLUSIONS: Prior employment in health-related positions was associated with both starting salary and experience-based wage growth among BSN-educated RNs. The higher wage return for those with a BSN may motivate non-RN healthcare workers to seek a BSN in their transition to RN jobs, which could help advancement toward the 80 % BSN workforce recommended by the U.S. Institute of Medicine.

OBJECTIVES: There is no systematic review on economic evaluations of telemedicine in Japan, despite over 1000 trials implemented. Our systematic review aims to examine whether Japan's telemedicine is cost-saving or cost-effective, examine the methodological rigorousness of the economic evaluations, and discuss future studies needed to improve telemedicine's financial sustainability. METHODS: We searched five databases, including two Japanese databases, to find peer-reviewed articles published between January 1, 2000 and December 31, 2014 in English and Japanese that performed economic evaluations of Japan's telemedicine programs. The methodological rigorousness of the economic analyses was assessed with a well-established checklist. We calculated the benefit-to-cost ratio (BCR) when a reviewed study reported related data but did not report the BCR. All cost values were adjusted to 2014 US dollars. RESULTS: Among the 17 articles identified, six studies reported on settings connecting physicians for specialist consultations, and eleven studies on settings connecting healthcare providers and patients at home. There are three cost-benefit analyses and three cost-minimization analyses. The remaining studies measured the benefit of telemedicine only, using medical expenditure saved or users' willingness-to-pay. There was substantial diversity in the methodological rigorousness. Studies on teledermatology and teleradiology indicated a favorable level of economic efficiency. Studies on telehomecare gave mixed results. One cost-benefit analysis on telehomecare indicated a low economic efficiency, partly due to public subsidy rules, e.g., a too short budget period. CONCLUSIONS: Overall, telemedicine programs in Japan were indicated to have a favorable level of economic efficiency. However, the scarcity of the economic literature indicates the need for further rigorous economic evaluation studies.

OBJECTIVE: Despite telemedicine's potential to improve patients' health outcomes and reduce costs in the ICU, hospitals have been slow to introduce telemedicine in the ICU due to high up-front costs and mixed evidence on effectiveness. This study's first aim was to conduct a cost-effectiveness analysis to estimate the incremental cost-effectiveness ratio of telemedicine in the ICU, compared with ICU without telemedicine, from the healthcare system perspective. The second aim was to examine potential cost saving of telemedicine in the ICU through probabilistic analyses and break-even analyses. DESIGN: Simulation analyses performed by standard decision models. SETTING: Hypothetical ICU defined by the U.S. literature. PATIENTS: Hypothetical adult patients in ICU defined by the U.S. literature. INTERVENTIONS: The intervention was the introduction of telemedicine in the ICU, which was assumed to affect per-patient per-hospital-stay ICU cost and hospital mortality. Telemedicine in the ICU operation costs included the telemedicine equipment-installation (start-up) costs with 5-year depreciation, maintenance costs, and clinician staffing costs. Telemedicine in the ICU effectiveness was measured by cumulative quality-adjusted life years for 5 years after ICU discharge. MEASUREMENTS AND MAIN RESULTS: The base case cost-effectiveness analysis estimated telemedicine in the ICU to extend 0.011 quality-adjusted life years with an incremental cost of $516 per patient compared with ICU without telemedicine, resulting in an incremental cost-effectiveness ratio of $45,320 per additional quality-adjusted life year (= $516/0.011). The probabilistic cost-effectiveness analysis estimated an incremental cost-effectiveness ratio of $50,265 with a wide 95% CI from a negative value (suggesting cost savings) to $375,870. These probabilistic analyses projected that cost saving is achieved 37% of 1,000 iterations. Cost saving is also feasible if the per-patient per-hospital-stay operational cost and physician cost were less than $422 and less than $155, respectively, based on break-even analyses. CONCLUSIONS: Our analyses suggest that telemedicine in the ICU is cost-effective in most cases and cost saving in some cases. The thresholds of cost and effectiveness, estimated by break-even analyses, help hospitals determine the impact of telemedicine in the ICU and potential cost saving.

BACKGROUND: School-located vaccination against influenza (SLV-I) has the potential to improve current suboptimal influenza immunization coverage for U.S. school-aged children. However, little is known about SLV-I's cost-effectiveness. The objective of this study is to establish the cost-effectiveness of SLV-I based on a two-year community-based randomized controlled trial (Year 1: 2009-2010 vaccination season, an unusual H1N1 pandemic influenza season, and Year 2: 2010-2011, a more typical influenza season). METHODS: We performed a cost-effectiveness analysis on a two-year randomized controlled trial of a Western New York SLV-I program. SLV-I clinics were offered in 21 intervention elementary schools (Year 1 n = 9,027; Year 2 n = 9,145 children) with standard-of-care (no SLV-I) in control schools (Year 1 n = 4,534 (10 schools); Year 2 n = 4,796 children (11 schools)). We estimated the cost-per-vaccinated child, by dividing the incremental cost of the intervention by the incremental effectiveness (i.e., the number of additionally vaccinated students in intervention schools compared to control schools). RESULTS: In Years 1 and 2, respectively, the effectiveness measure (proportion of children vaccinated) was 11.2 and 12.0 percentage points higher in intervention (40.7 % and 40.4 %) than control schools. In year 2, the cost-per-vaccinated child excluding vaccine purchase ($59.88 in 2010 US $) consisted of three component costs: (A) the school costs ($8.25); (B) the project coordination costs ($32.33); and (C) the vendor costs excluding vaccine purchase ($16.68), summed through Monte Carlo simulation. Compared to Year 1, the two component costs (A) and (C) decreased, while the component cost (B) increased in Year 2. The cost-per-vaccinated child, excluding vaccine purchase, was $59.73 (Year 1) and $59.88 (Year 2, statistically indistinguishable from Year 1), higher than the published cost of providing influenza vaccination in medical practices ($39.54). However, taking indirect costs (e.g., averted parental costs to visit medical practices) into account, vaccination was less costly in SLV-I ($23.96 in Year 1, $24.07 in Year 2) than in medical practices. CONCLUSIONS: Our two-year trial's findings reinforced the evidence to support SLV-I as a potentially favorable system to increase childhood influenza vaccination rates in a cost-efficient way. Increased efficiencies in SLV-I are needed for a sustainable and scalable SLV-I program.

BACKGROUND: Comprehensive economic evaluations have not been conducted on telemedicine consultations to children in rural emergency departments (EDs). OBJECTIVE: We conducted an economic evaluation to estimate the cost, effectiveness, and return on investment (ROI) of telemedicine consultations provided to health care providers of acutely ill and injured children in rural EDs compared with telephone consultations from a health care payer prospective. METHODS: We built a decision model with parameters from primary programmatic data, national data, and the literature. We performed a base-case cost-effectiveness analysis (CEA), a probabilistic CEA with Monte Carlo simulation, and ROI estimation when CEA suggested cost-saving. The CEA was based on program effectiveness, derived from transfer decisions following telemedicine and telephone consultations. RESULTS: The average cost for a telemedicine consultation was $3641 per child/ED/year in 2013 US dollars. Telemedicine consultations resulted in 31% fewer patient transfers compared with telephone consultations and a cost reduction of $4662 per child/ED/year. Our probabilistic CEA demonstrated telemedicine consultations were less costly than telephone consultations in 57% of simulation iterations. The ROI was calculated to be 1.28 ($4662/$3641) from the base-case analysis and estimated to be 1.96 from the probabilistic analysis, suggesting a $1.96 return for each dollar invested in telemedicine. Treating 10 acutely ill and injured children at each rural ED with telemedicine resulted in an annual cost-savings of $46,620 per ED. LIMITATIONS: Telephone and telemedicine consultations were not randomly assigned, potentially resulting in biased results. CONCLUSIONS: From a health care payer perspective, telemedicine consultations to health care providers of acutely ill and injured children presenting to rural EDs are cost-saving (base-case and more than half of Monte Carlo simulation iterations) or cost-effective compared with telephone consultations.

BACKGROUND: The U.S. policy goals regarding influenza vaccination coverage rate among the elderly include the increase in the coverage rate and the elimination of disparities across racial/ethnic groups. OBJECTIVE: To examine the potential effectiveness of a television (TV) campaign to increase seasonal influenza vaccination among the elderly. METHODS: We estimated the incremental cost-effectiveness ratio (ICER, defined as incremental cost per additionally vaccinated Medicare individual) of a hypothetical nationwide TV campaign for influenza vaccination compared with no campaign. We measured the effectiveness of the nationwide TV campaign (advertised once a week at prime time for 30 seconds) during a 17-week influenza vaccination season among four racial/ethnic elderly groups (N=39 million): non-Hispanic white (W), non-Hispanic African American (AA), English-speaking Hispanic (EH), and Spanish-speaking Hispanic (SH). RESULTS: The hypothetical campaign cost was $5,960,000 (in 2012 US dollars). The estimated campaign effectiveness ranged from -1.1% (the SH group) to 1.42% (the W group), leading to an increased disparity in influenza vaccination among non-Hispanic white and non-Hispanic African American (W-AA) groups (0.6 percentage points), W-EH groups (0.1 percentage points), and W-SH groups (1.5 percentage points). The estimated ICER was $23.54 (95% confidence interval $14.21-$39.37) per additionally vaccinated Medicare elderly in a probabilistic analysis. Race/ethnicity-specific ICERs were lowest among the EH group ($22.27), followed by the W group ($22.47) and the AA group ($30.55). The nationwide TV campaign was concluded to be reasonably cost-effective compared with a benchmark intervention (with ICER $44.39 per vaccinated individual) of a school-located vaccination program. Break-even analyses estimated the maximum acceptable campaign cost to be $14,870,000, which was comparable to the benchmark ICER. CONCLUSIONS: The results could justify public expenditures on the implementation of a future nationwide TV campaign, which should include multilingual campaigns, for promoting seasonal influenza vaccination.

While persistent racial/ethnic disparities in influenza vaccination have been reported among the elderly, characteristics contributing to disparities are poorly understood. This study aimed to assess characteristics associated with racial/ethnic disparities in influenza vaccination using a nonlinear Oaxaca-Blinder decomposition method. We performed cross-sectional multivariable logistic regression analyses for which the dependent variable was self-reported receipt of influenza vaccine during the 2010-2011 season among community dwelling non-Hispanic African-American (AA), non-Hispanic White (W), English-speaking Hispanic (EH) and Spanish-speaking Hispanic (SH) elderly, enrolled in the 2011 Medicare Current Beneficiary Survey (MCBS) (un-weighted/weighted N=6,095/19.2 million). Using the nonlinear Oaxaca-Blinder decomposition method, we assessed the relative contribution of seventeen covariates - including socio-demographic characteristics, health status, insurance, access, preference regarding healthcare, and geographic regions - to disparities in influenza vaccination. Unadjusted racial/ethnic disparities in influenza vaccination were 14.1 percentage points (pp) (W-AA disparity, p<0.001), 25.7 pp (W-SH disparity, p<0.001) and 0.6 pp (W-EH disparity, p>.8). The Oaxaca-Blinder decomposition method estimated that the unadjusted W-AA and W-SH disparities in vaccination could be reduced by only 45% even if AA and SH groups become equivalent to Whites in all covariates in multivariable regression models. The remaining 55% of disparities were attributed to (a) racial/ethnic differences in the estimated coefficients (e.g., odds ratios) in the regression models and (b) characteristics not included in the regression models. Our analysis found that only about 45% of racial/ethnic disparities in influenza vaccination among the elderly could be reduced by equalizing recognized characteristics among racial/ethnic groups. Future studies are needed to identify additional modifiable characteristics causing disparities in influenza vaccination.

School-located vaccination against influenza (SLV-I) has been suggested to help meet the need for annual vaccination of large numbers of school-aged children with seasonal influenza vaccine. However, little is known about the cost and cost-effectiveness of SLV-I. We conducted a cost-analysis and a cost-effectiveness analysis based on a randomized controlled trial (RCT) of an SLV-I program implemented in Monroe County, New York during the 2009-2010 vaccination season. We hypothesized that SLV-I is more cost effective, or less-costly, compared to a conventional, office-located influenza vaccination delivery. First and second SLV-I clinics were offered in 21 intervention elementary schools (n=9027 children) with standard of care (no SLV-I) in 11 control schools (n=4534 children). The direct costs, to purchase and administer vaccines, were estimated from our RCT. The effectiveness measure, receipt of ≥1 dose of influenza vaccine, was 13.2 percentage points higher in SLV-I schools than control schools. The school costs ($9.16/dose in 2009 dollars) plus project costs ($23.00/dose) plus vendor costs excluding vaccine purchase ($19.89/dose) was higher in direct costs ($52.05/dose) than the previously reported mean/median cost [$38.23/$21.44 per dose] for providing influenza vaccination in pediatric practices. However SLV-I averted parent costs to visit medical practices ($35.08 per vaccine). Combining direct and averted costs through Monte Carlo Simulation, SLV-I costs were $19.26/dose in net costs, which is below practice-based influenza vaccination costs. The incremental cost-effectiveness ratio (ICER) was estimated to be $92.50 or $38.59 (also including averted parent costs). When additionally accounting for the costs averted by disease prevention (i.e., both reduced disease transmission to household members and reduced loss of productivity from caring for a sick child), the SLV-I model appears to be cost-saving to society, compared to "no vaccination". Our findings support the expanded implementation of SLV-I, but also the need to focus on efficient delivery to reduce direct costs.

OBJECTIVE: To assess the impact of a managed care-based patient reminder/recall system on immunization rates and preventive care visits among low-income adolescents. METHODS: We conducted a randomized controlled trial between December 2009 and December 2010 that assigned adolescents aged 11-17 years to one of three groups: mailed letter, telephone reminders, or control. Publicly insured youths (n = 4115) were identified in 37 participating primary care practices. The main outcome measures were immunization rates for routine vaccines (meningococcus, pertussis, HPV) and preventive visit rates at study end. RESULTS: Intervention and control groups were similar at baseline for demographics, immunization rates, and preventive visits. Among adolescents who were behind at the start, immunization rates at study end increased by 21% for mailed (P < .01 vs control), 17% for telephone (P < .05), and 13% for control groups. The proportion of adolescents with a preventive visit (within 12 months) was: mailed (65%; P < .01), telephone (63%; P < .05), and controls (59%). The number needed to treat for an additional fully vaccinated adolescent was 14 for mailed and 25 for telephone reminders; for an additional preventive visit, it was 17 and 29. The intervention cost $18.78 (mailed) or $16.68 (phone) per adolescent per year to deliver. The cost per additional adolescent fully vaccinated was $463.99 for mailed and $714.98 for telephone; the cost per additional adolescent receiving a preventive visit was $324.75 and $487.03. CONCLUSIONS: Managed care-based mail or telephone reminder/recall improved adolescent immunizations and preventive visits, with modest costs and modest impact.

Studies have demonstrated that low-income families often have disproportionately high utilization of emergency department (ED) and hospital services, and low utilization of preventive visits. A possible contributing factor is that some mothers may not respond optimally to their infants' health needs, either due to their own responsiveness or due to the child's ability to send cues. These mother-child interactions are measurable and amenable to change. We examined the associations between mother-child interactions and child healthcare utilization among low-income families. We analyzed data from the Nurse-Family Partnership trial in Memphis, TN control group (n = 432). Data were collected from child medical records (birth to 24 months), mother interviews (12 and 24 months postpartum), and observations of mother-child interactions (12 months postpartum). We used logistic and ordered logistic regression to assess independent associations between mother-child interactions and child healthcare utilization measures: hospitalizations, ED visits, sick-child visits to primary care, and well-child visits. Better mother-child interactions, as measured by mother's responsiveness to her child, were associated with decreased hospitalizations (OR: 0.51; 95% CI: 0.32, 0.81), decreased ambulatory-care-sensitive ED visits (OR: 0.65, 95% CI: 0.44, 0.96), and increased well-child visits (OR: 1.55, 95% CI: 1.06, 2.28). Mother's responsiveness to her child was associated with child healthcare utilization. Interventions to improve mother-child interactions may be appropriate for mother-child dyads in which child healthcare utilization appears unbalanced with inadequate primary care and excess urgent care. Recognition of these interactions may also improve the care clinicians provide for families.

The objective of this study is to examine the role of maternal self-efficacy as a potential mediator between maternal depression and child hospitalizations in low-income families. We analyzed data from 432 mother-child pairs who were part of the control-group for the Nurse-Family Partnership trial in Memphis, TN. Low-income urban, mostly minority women were interviewed 12 and 24 months after their first child's birth and their child's medical records were collected from birth to 24 months. We fit linear and ordered logistic regression models to test for mediation. We also tested non-linear relationships between the dependent variable (child hospitalization) and covariates (depressive symptoms and self-efficacy). Elevated depressive symptoms (OR: 1.70; 90% CI: 1.05, 2.74) and lower maternal self-efficacy (OR: 0.674; 90% CI: 0.469, 0.970) were each associated with increased child hospitalizations. When both maternal self-efficacy and depressive symptoms were included in a single model, the depressive symptoms coefficient decreased significantly (OR decreased by 0.13, P = 0.069), supporting the hypothesis that self-efficacy serves as a mediator. A non-linear, inverse-U shaped relationship between maternal self-efficacy and child hospitalizations was supported: lower compared to higher self-efficacy was associated with more child hospitalizations (P = 0.039), but very low self-efficacy was associated with fewer hospitalizations than low self-efficacy (P = 0.028). In this study, maternal self-efficacy appears to be a mediator between maternal depression and child hospitalizations. Further research is needed to determine if interventions specifically targeting self-efficacy in depressed mothers might decrease child hospitalizations.

Japan shows the advantages and limitations of pursuing universal health coverage by establishment of employee-based and community-based social health insurance. On the positive side, almost everyone came to be insured in 1961; the enforcement of the same fee schedule for all plans and almost all providers has maintained equity and contained costs; and the co-payment rate has become the same for all, except for elderly people and children. This equity has been achieved by provision of subsidies from general revenues to plans that enrol people with low incomes, and enforcement of cross-subsidisation among the plans to finance the costs of health care for elderly people. On the negative side, the fragmentation of enrolment into 3500 plans has led to a more than a three-times difference in the proportion of income paid as premiums, and the emerging issue of the uninsured population. We advocate consolidation of all plans within prefectures to maintain universal and equitable coverage in view of the ageing society and changes in employment patterns. Countries planning to achieve universal coverage by social health insurance based on employment and residential status should be aware of the limitations of such plans.

Annual epidemics of seasonal influenza occur during autumn and winter in temperate regions and have imposed substantial public health and economic burdens. At the global level, these epidemics cause about 3-5 million severe cases of illness and about 0.25-0.5 million deaths each year. Although annual vaccination is the most effective way to prevent the disease and its severe outcomes, influenza vaccination coverage rates have been at suboptimal levels in many countries. For instance, the coverage rates among the elderly in 20 developed nations in 2008 ranged from 21% to 78% (median 65%). In the U.S., influenza vaccination levels among elderly population appeared to reach a "plateau" of about 70% after the late 1990s, and levels among child populations have remained at less than 50%. In addition, disparities in the coverage rates across subpopulations within a country present another important public health issue. New approaches are needed for countries striving both to improve their overall coverage rates and to eliminate disparities. This review article aims to describe a broad conceptual framework of vaccination, and to illustrate four potential determinants of influenza vaccination based on empirical analyses of U.S. nationally representative populations. These determinants include the ongoing influenza epidemic level, mass media reporting on influenza-related topics, reimbursement rate for providers to administer influenza vaccination, and vaccine supply. It additionally proposes specific policy implications, derived from these empirical analyses, to improve the influenza vaccination coverage rate and associated disparities in the U.S., which could be generalizable to other countries.

BACKGROUND: The impact of vaccine shortages on disparities in influenza vaccination is uncertain. PURPOSE: The objective of this research was to examine the association between influenza vaccine supply and racial/ethnic disparities in vaccination rates among elderly Medicare beneficiaries. METHODS: Cross-sectional multivariable logistic regression analyses were performed in 2010 to examine whether racial/ethnic disparities in vaccination rates changed across two consecutive seasons: from (Period 1) 2000-2001 and 2001-2002 seasons through (Period 4) 2003-2004 and 2004-2005 seasons. Self-reported receipt of influenza vaccine across consecutive years was examined among community-dwelling non-Hispanic African-American (AA); non-Hispanic white (W); English-speaking Hispanic (EH); and Spanish-speaking Hispanic (SH) elderly enrolled in the Medicare Current Beneficiary Survey (unweighted n=2306-2504, weighted n=8.23-8.99 million for Periods 1 through 4). RESULTS: During Periods 1 and 2, when vaccine supply increased nationally, adjusted racial/ethnic disparities in the influenza vaccination rate decreased by 1.8%-7.4% (W-AA disparity); 4.5%-6.6% (W-EH disparity); and 6.6%-11% (W-SH disparity) (all p<0.001). During Period 4, when vaccine supply declined, adjusted disparities in vaccination rates increased by 2.3% (W-AA disparity) and 6.1% (W-EH disparity) but decreased by 6.6% (W-SH disparity) probably due to a "floor effect" (constant low rates among SH; all p<0.001). CONCLUSIONS: Improved vaccine supply was generally associated with reduced racial/ethnic disparities in influenza vaccination rates, whereas worse supply was associated with increased disparities. To avoid future widening of racial health disparities, policy options include stabilizing the vaccine supply and preferential delivery of vaccines to safety-net providers serving AA and Hispanic populations during a shortage.

OBJECTIVE: We examined associations between influenza vaccination rates and Medicaid reimbursement rates for vaccine administration among poor children who were eligible for Medicaid (<100% of the federal poverty level in all states). METHODS: We analyzed 3 consecutive National Immunization Surveys (NISs) to assess influenza vaccination rates among nationally representative children 6 to 23 months of age during the 2005-2006 (unweighted N = 12 885), 2006-2007 (unweighted N = 9238), and 2007-2008 (unweighted N = 11 785) influenza seasons (weighted N = 3.3-4.0 million per season). We categorized children into 3 income levels (poor, near-poor, or nonpoor). We performed analyses with full influenza vaccination as the dependent variable and state Medicaid reimbursement rates (continuous covariate ranging from $2 to $17.86 per vaccination) and terms with income levels as key covariates. RESULTS: In total, 21.0%, 21.3%, and 28.9% of all US children and 11.7%, 11.6%, and 18.8% of poor children were fully vaccinated in the 2006, 2007, and 2008 NISs, respectively. Multivariate analyses of all 3 seasons found positive significant (all P < .05) associations between state-level Medicaid reimbursement and influenza vaccination rates among poor children. A $10 increase, from $8 per influenza vaccination (the US average) to $18 (the highest state reimbursement), in the Medicaid reimbursement rate was associated with 6.0-, 9.2-, and 6.4-percentage point increases in full vaccination rates among poor children in the 2006, 2007, and 2008 NIS analyses, respectively. CONCLUSION: Medicaid reimbursement rates are strongly associated with influenza vaccination rates.

OBJECTIVE: To measure the association between mass media coverage on flu-related topics and influenza vaccination, regarding timing and annual vaccination rates, among the nationally representative community-dwelling elderly. DATA SOURCE: Years 1999, 2000, and 2001 Medicare Current Beneficiary Survey. STUDY DESIGN: Cross-sectional survival analyses during each of three influenza vaccination seasons between September 1999 and December 2001. The outcome variable was daily vaccine receipt. We measured daily media coverage by counting the number of television program transcripts and newspaper/wire service articles, including keywords of influenza/flu and vaccine/shot shortage/delay. All models' covariates included three types of media, vaccine supply, and regional/individual factors. PRINCIPAL FINDINGS: Influenza-related reports in all three media sources had a positive association with earlier vaccination timing and annual vaccination rate. Four television networks' reports had most consistent positive effects in all models, for example, shifting the mean vaccination timing earlier by 1.8-4.1 days (p<.001) or increasing the annual vaccination rate by 2.3-7.9 percentage points (p<.001). These effects tended to be greater when reported in a headline rather than in text only and if including additional keywords, for example, vaccine shortage/delay. CONCLUSIONS: Timing and annual receipt of influenza vaccination appear to be influenced by media coverage, particularly by headlines and specific reports on shortage/delay.

OBJECTIVES: The goals were to estimate nationally representative pediatric practices' costs of providing influenza vaccination during the 2006-2007 season and to simulate the costs pediatric practices might incur when implementing universal influenza vaccination for US children aged 6 months to 18 years. METHODS: We surveyed a stratified, random sample of New York State pediatric practices (N = 91) to obtain information from physicians and office managers about all practice resources associated with provision of influenza vaccination. We estimated vaccination costs for 2 practice sizes (small and large) and 3 geographic areas (urban, suburban, and rural). We adjusted these data to obtain national estimates of the total practice cost (in 2006 dollars) for providing 1 influenza vaccination to children aged 6 months to 18 years. RESULTS: Among all respondents, the median total cost per vaccination was $28.62 (interquartile range: $18.67-45.28). The median component costs were as follows: clinical personnel labor costs, $2.01; nonclinical personnel labor costs, $7.96; all other (overhead) costs, $10.43. Vaccine purchase costs averaged $8.22. Smaller practices and urban practices had higher costs than larger or suburban practices. With the assumption of vaccine administration reimbursement for all Vaccines for Children (VFC)-eligible children at the current Medicaid median of $8.40, the financial loss across all US pediatric practices through delivery of VFC vaccines would be $98 million if one third of children received influenza vaccine. CONCLUSION: The total cost for pediatric practices to provide influenza vaccination is high, varies according to practice characteristics, and exceeds the average VFC reimbursement.

OBJECTIVES: We assessed short-term responsiveness of influenza vaccine demand to variation in timing and severity of influenza epidemics since 2000. We tested the hypothesis that weekly influenza epidemic activity is associated with annual and daily influenza vaccine receipt. METHODS: We conducted cross-sectional survival analyses from the 2000-2001 to 2004-2005 influenza seasons among community-dwelling elderly using the Medicare Current Beneficiary Survey (unweighted n = 2280-2822 per season; weighted n = 7.7-9.7 million per season). The outcome variable was daily vaccine receipt. Covariates included the biweekly changes of epidemic and vaccine supply at 9 census-region levels. RESULTS: In all 5 seasons, biweekly epidemic change was positively associated with overall annual vaccination (e.g., 2.7% increase in 2003-2004 season) as well as earlier vaccination timing (P < .01). For example, unvaccinated individuals were 5%-29% more likely to receive vaccination after a 100% biweekly epidemic increase. CONCLUSIONS: Accounting for short-term epidemic responsiveness in predicting demand for influenza vaccination may improve vaccine distribution and the annual vaccination rate, and might assist pandemic preparedness planning.

Objective: To assess the cost effectiveness of newborn screening for congenital adrenal hyperplasia (CAH) in the U.S. newborn population. Methods: We constructed a decision model to estimate the incremental cost-effectiveness ratio (ICER) of CAH screening compared to a strategy of no screening. Two types of cost effectiveness analyses (CEA) were conducted to measure ICER as net cost per life year (LY): (1) traditional CEA with sensitivity and scenario analyses, and (2) probabilistic CEA. Results: ICERs for (1) base-case analysis in traditional CEA and (2) probabilistic CEA were USD 292,000 and USD 255,700 per LY saved in 2005 USD, respectively. ICERs were particularly sensitive to assumptions regarding the mortality rate for the salt wasting type of CAH, in a range from 2 to 9%. The ICERs for best-case and worst-case scenarios were USD 30,900 and USD 2.9 million per LY saved, respectively. Conclusions: Using common benchmarks for cost effectiveness, our results indicate that CAH screening would be unlikely to be considered cost effective unless assumptions favorable to screening were adopted, although it could meet economic criteria used to assess U.S. regulatory policies. A limitation is that the analysis excludes outcomes such as correct assignment of gender and quality of life.

OBJECTIVE: To estimate the additional primary care visits needed for universal influenza vaccination of all US children and adolescents if all vaccinations occurred in primary care settings. DESIGN: Cross-sectional design. SETTING: Well-child care and other visits to primary care practices from the 2003-2004 Medical Expenditure Panel Survey. PARTICIPANTS: Children aged 5 to 18 years (n = 3047) with a usual source of care. Main Outcome Measure Percentage of children needing 0, 1, or 2 additional visits to be immunized against influenza in a 3-, 4-, or 5-month vaccination window. RESULTS: In a 3-month window, if only well-child care visits were used for first immunization, 97% of 5- and 6-year-olds and 98% of 7- and 8-year-olds would need 1 or 2 additional visits for complete vaccination; 95% of 9- to 18-year-olds would need 1 visit. If instead all visits were used for immunization, 90% of 5- and 6-year-olds and 91% of 7- and 8-year-olds would need 1 or 2 visits; 78% of 9- to 18-year-olds would need 1 visit. Expanding the window to 4 or 5 months slightly reduces the need for additional visits. Nationally, using all opportunities for vaccination, 42 million additional visits would be needed in a generous 5-month window. CONCLUSIONS: Most children and adolescents would need additional visits for universal influenza vaccination, even if all existing visits were used as vaccination opportunities. Efficient methods for vaccinating large numbers of children and adolescents are needed if primary care practices are to provide influenza vaccine for all children.

OBJECTIVE: To assess whether estimates of the effectiveness of influenza vaccination in reducing rates of hospitalizations and all-cause mortality derived from cross-sectional data could be improved by applying the instrumental variable (IV) method to data representing the community-dwelling elderly population in the United States in order to adjust for self-selection bias. METHODS: Secondary data analysis, using the 1996-97 Medicare Current Beneficiary Survey data. First, using single-equation probit regressions this study analyzed influenza-related hospitalization and death due to all causes predicted by vaccination status, which was measured by claims or survey data. Second, to adjust for potential self-selection of the vaccine receipt, for example, higher vaccination rates among high-risk individuals, bivariate probit (BVP) models and two-stage least squares (2SLS) models were employed. The IV was having either arthritis or gout. RESULTS: In single-equation probit models, vaccination appeared to be ineffective or even to increase the probability of adverse outcomes. Based on BVP and 2SLS models, vaccination was demonstrated to be effective in reducing influenza-related hospitalization by at least 31%. The BVP model results implied significant self-selection in the single-equation probit models. CONCLUSIONS: Adjusting for self-selection, BVP analyses yielded vaccine effectiveness estimates for a nationally representative cross-sectional sample of the community-dwelling elderly population that are consistent with previous estimates based on randomized controlled trials, prospective cohort studies, and meta-analyses. This result suggests that analyses with 2SLS and BVP in particular may be useful for the analysis of observational data regarding prevention in which self-selection is an important potential source of bias.

New guidelines recommend different influenza vaccination timing for different subpopulations due to the limited availability of flu shots (FS). This study's objectives are to develop a theoretical model to demonstrate why some individuals choose to receive an early FS while others choose a late FS and to empirically explore the determinants of vaccination timing. Empirical results generally supported the theoretical results. Individuals vary their FS timing in response to variations in perceived risks, chronic condition levels reflecting their risk of influenza infection, and opportunity costs, measured by the presence of medical care other than an FS.

OBJECTIVE: To quantify the effects of informal caregiver availability and public funding on formal long-term care (LTC) expenditures in developed countries. DATA SOURCE/STUDY SETTING: Secondary data were acquired for 15 Organization for Economic Cooperation and Development (OECD) countries from 1970 to 2000. STUDY DESIGN: Secondary data analysis, applying fixed- and random-effects models to time-series cross-sectional data. Outcome variables are inpatient or home heath LTC expenditures. Key explanatory variables are measures of the availability of informal caregivers, generosity in public funding for formal LTC, and the proportion of the elderly population in the total population. DATA COLLECTION/EXTRACTION METHOD: Aggregated macro data were obtained from OECD Health Data, United Nations Demographic Yearbooks, and U.S. Census Bureau International Data Base. PRINCIPAL FINDINGS: Most of the 15 OECD countries experienced growth in LTC expenditures over the study period. The availability of a spouse caregiver, measured by male-to-female ratio among the elderly, is associated with a $28,840 (1995 U.S. dollars) annual reduction in formal LTC expenditure per additional elderly male. Availability of an adult child caregiver, measured by female labor force participation and full-time/part-time status shift, is associated with a reduction of $310 to $3,830 in LTC expenditures. These impacts on LTC expenditure vary across countries and across time within a country. CONCLUSIONS: The availability of an informal caregiver, particularly a spouse caregiver, is among the most important factors explaining variation in LTC expenditure growth. Long-term care policies should take into account behavioral responses: decreased public funding in LTC may lead working women to leave the labor force to provide more informal care.