Understanding post-stroke spasticity (PSS) treatment in everyday clinical practice may guide improvements in patient care.

This was a retrospective cohort study that used population-level administrative data. Adults (aged ≥18 years) who initiated PSS treatment (defined by the first PSS clinic visit, focal botulinum toxin injection, or anti-spasticity medication dispensation [baclofen, dantrolene and tizanidine] with none of these treatments occurring during the 2 years before the stroke) were identified between 2012 and 2019 in Alberta, Canada. Spasticity treatment use, time to treatment start and type of prescribing/treating physician were measured. Descriptive statistics were performed.

Within the cohort (n = 1,079), the most common PSS treatment was oral baclofen (initial treatment: 60.9%; received on/after the initial treatment date up to March 31, 2020: 69.0%), largely prescribed by primary care physicians (77.6%) and started a median of 348 (IQR 741) days after the stroke. Focal botulinum toxin (23.3%; 37.7%) was largely prescribed by physiatrists (72.2%) and started 311 (IQR 446) days after the stroke; spasticity clinic visits (18.6%; 23.8%) were also common.

We found evidence of gaps in provision of spasticity management in persons with PSS including overuse of systemic oral baclofen (that has common adverse side effects and lacks evidence of effectiveness in PSS) and potential underuse of focal botulinum toxin injections. Further investigation and strategies should be pursued to improve alignment of PSS treatment with guideline recommendations that in turn will support better outcomes for those with PSS.

Minoritised young people face a double burden of discrimination through increased risk of stress and differential treatment access. However, acute care pathways for minoritised young people with urgent mental health needs are poorly understood.

To explore variation in stress-related presentations (SRPs) to acute hospitals across racial-ethnic groups in England.

We examined rates, distribution, duration and types of SRPs across racial-ethnic groups in a retrospective cohort of 11- to 15-year-olds with one or more emergency hospital admissions between April 2014 and March 2020. SRPs were defined as emergency admissions for potentially psychosomatic symptoms, self-harm and internalising, externalising and thought disorders.

White British (8–38 per 1000 births) and Mixed White–Black (9–42 per 1000 births) young people had highest rates of SRPs, whereas Black African (5–14 per 1000 births), Indian (6–19 per 1000 births) and White other (4–19 per 1000 births) young people had the lowest rates of SRPs. The proportion of readmissions were highest for Pakistani (47.7%), White British (41.4%) and Mixed White–Black (41.3%) groups. Black Other (36.4%) and White Other (35.8%) groups had the lowest proportions of readmissions. The proportion of admission durations ≥3 days was higher for Black Other (16.6%), Bangladeshi (16.3%), Asian Other (15.9%) and Black Caribbean (15.8%) groups than their White British (11.9%) and Indian (11.8%) peers. The type of SRPs varied across racial-ethnic groups.

Patterns of SRP admissions systematically differed across racial-ethnic groups, indicative of inequitable triage, assessment and treatment processes. These findings highlight the need for implementation of race equality frameworks to address structural racism in healthcare pathways.

We aimed to (1) report updated estimates of direct healthcare costs for people living with MS (pwMS), (2) contrast costs to a control population and (3) explore differences between disability levels among pwMS.

Administrative data were used to identify adult pwMS (MS cohort) and without (control cohort) in Alberta, Canada; disability level (based on the Expanded Disability Status Scale) among pwMS was estimated. One- and two-part generalized linear models with gamma distribution were used to estimate the incremental direct healthcare cost (2021 $CDN) of MS during a 1-year observation period.

Adjusting for confounders, the total healthcare cost ratio was higher in the MS cohort (n = 13,089) versus control (n = 150,080) (5.24 [95% CI: 5.08, 5.41]) with a predicted incremental cost of $15,016 (95% CI: $14,497, $15,535) per person-year. Among the MS cohort, total predicted direct healthcare costs were higher with greater disability, $14,430 (95% CI: $13,980, $14,880) to $58,697 ($51,514, $65,879) per person-year in mild and severe disability, respectively. The primary health resource cost component shifted from disease-modifying therapies in mild disability to supportive care in moderate and severe disability.

Adult pwMS had greater direct healthcare costs than those without. Extrapolating to the population level (where 14,485 adult pwMS were identified in the study), it is estimated that $218 million per year in healthcare costs may be attributable to MS in Alberta. The significantly larger economic impact associated with greater disability underscores the importance of preventing or delaying disease progression and functional impairment in MS.

Understanding disease-modifying therapy (DMT) use and healthcare resource utilization by different geographical areas among people living with multiple sclerosis (pwMS) may identify care gaps that can be used to inform policies and practice to ensure equitable care.

Administrative data was used to identify pwMS on April 1, 2017 (index date) in Alberta. DMT use and healthcare resource utilization were compared between those who resided in various geographical areas over a 2-year post-index period; simple logistic regression was applied.

Among the cohort (n = 12,338), a higher proportion of pwMS who resided in urban areas (versus rural) received ≥ 1 DMT dispensation (32.3% versus 27.4%), had a neurologist (67.7% versus 63.9%), non-neurologist specialist (88.3% versus 82.9%), ambulatory care visit (87.4% versus 85.3%), and MS tertiary clinic visit (59.2% versus 51.7%), and a lower proportion had an emergency department (ED) visit (46.3% versus 62.4%), and hospitalization (20.4% versus 23.0%). Across the provincial health zones, there were variations in DMT selection, and a higher proportion of pwMS who resided in the Calgary health zone, where care is managed by MS tertiary clinic neurologists, had an outpatient visit to a neurologist or MS tertiary clinic versus those who resided in other zones where delivery of MS-related care is more varied.

Urban/rural inequalities in DMT use and healthcare resource utilization appear to exist among pwMS in Alberta. Findings suggest the exploration of barriers with consequent strategies to increase access to DMTs and provide timely outpatient MS care management, particularly for those pwMS residing in rural areas.

Deaths from suicides, drug poisonings, and alcohol-related diseases (‘deaths of despair’) are well-documented among working-age Americans, and have been hypothesized to be largely specific to the U.S. However, support for this assertion–and associated policies to reduce premature mortality–requires tests concerning these deaths in other industrialized countries, with different institutional contexts. We tested whether the concentration and accumulation of health and social disadvantage forecasts deaths of despair, in New Zealand and Denmark.

We used nationwide administrative data. Our observation period was 10 years (NZ = July 2006–June 2016, Denmark = January 2007–December 2016). We identified all NZ-born and Danish-born individuals aged 25–64 in the last observation year (NZ = 1 555 902, Denmark = 2 541 758). We ascertained measures of disadvantage (public-hospital stays for physical- and mental-health difficulties, social-welfare benefit-use, and criminal convictions) across the first nine years. We ascertained deaths from suicide, drugs, alcohol, and all other causes in the last year.

Deaths of despair clustered within a population segment that disproportionately experienced multiple disadvantages. In both countries, individuals in the top 5% of the population in multiple health- and social-service sectors were at elevated risk for deaths from suicide, drugs, and alcohol, and deaths from other causes. Associations were evident across sex and age.

Deaths of despair are a marker of inequalities in countries beyond the U.S. with robust social-safety nets, nationwide healthcare, and strong pharmaceutical regulations. These deaths cluster within a highly disadvantaged population segment identifiable within health- and social-service systems.

The COVID-19 pandemic and associated lockdowns were predicted to have a major impact on suicidal behaviour, including self-harm. However, current studies have produced contradictory findings with limited trend data.

Nine years of linked individual-level administrative data were utilised to examine changes in hospital-presenting self-harm and ideation (thoughts of self-harm or suicide) before and during the pandemic.

National self-harm registry data were linked to demographic and socioeconomic indicators from healthcare registration records (n = 1 899 437). Monthly presentations of self-harm or ideation were split (pre-COVID-19 restrictions: April 2012 to February 2020; and during restrictions: March to September 2020). Auto-regressive integrated moving average (ARIMA) models were trained in R taking into consideration trends and seasonal effects. Forecast (‘expected’) monthly values were compared with ‘actual’ values, stratified by demographic factors and method of harm.

The number of individuals presenting with self-harm or ideation dropped significantly at the beginning of the pandemic (March–May 2020), before returning mostly to expected trends from June 2020. Stratified analysis showed similar presentation trends across most demographic subgroups except for those aged over 65 years, living alone or in affluent areas, where presentations remained unaffected, and those aged under 16 years, where numbers presenting with self-harm or ideation increased above expected levels.

Although population trends show an overall drop in presentations before a return to ‘normal’ from June 2020, the demographic profile of those presenting with self-harm or ideation varied significantly, with increases in children under the age of 16 years. This highlights important potential target groups who may have been most negatively affected by the pandemic.

Uterine cancer is the most common gynecologic malignant neoplasm in developed countries. While depression is up to 3-5 times more common in patients with cancer than in the general population, literature is still limited regarding the relation between Endometrial Cancer and depression.

To analyze Depression among Endometrial Cancer hospitalizations in mainland Portuguese public hospitals (2008-2015).

A retrospective observational study was conducted using administrative data from all hospitalizations in Portuguese mainland public hospitals between 2008-2015. All women’s hospitalizations(≥18 years) with a primary diagnosis of Endometrial Cancer (ICD-9-CM 182.x) were selected. Secondary diagnosis of depression was identified with ICD-9-CM 296.2x, 296.3x and 311x codes. Surgical procedures codes 68.4x, 65.6x, 40.3x, 40.5x, 68.6x, 68.9x and 68.8x were used to divide the hospitalizations into surgical vs non-surgical. Groups were compared with Pearson Chi-square test and crude odds ratio(OR) was used to estimate the association between surgery and depression.

From 10227 hospitalizations with a primary diagnosis of Endometrial Cancer, 533 had a registry of depression(5.2%). Annual depression frequency rose from 2.0% (2008) to 8.3% (2015). Among patients with a record of depression, 73.2% had surgery. Women who had surgery were significantly more likely to have registered depression (p<0.001). The OR for depression in surgical vs non-surgical patients was 1.73 (95%IC:1.42-2.10).

Patients hospitalized due to Endometrial Cancer and submitted to surgery had almost two-fold more risk of having a registry of depression. This trend reinforces the importance of early depression screening of these patients, enabling the implementation of timely therapeutic strategies before and after surgery.

No significant relationships.

Prevalence estimates of child and youth mental disorder and mental health-related service contacts are needed for policy formulation, research, advocacy and resource allocation. Our aim is to compare prevalence estimates of child and youth mental disorder and mental health-related service contacts derived from general population survey data v. linked administrative health data.

Provincially representative 2014 Ontario Child Health Study data were linked to administrative health records for 5563 children and youth aged 4–17 in Ontario. Emotional disorders (mood and anxiety) and attention-deficit/hyperactivity disorder were assessed using a standardised diagnostic interview in the survey and using diagnostic codes in administrative health data. Physician-based mental health-related service contacts were assessed using parent self-reports from the survey and administrative data related to mental health-related diagnostic codes. Prevalence estimates were calculated and compared based on one-sample z-tests and ratios of survey data to administrative data-based prevalence. Sensitivity, specificity and agreement between classifications were compared using κ. Prevalence estimates were calculated by age, sex and geography sub-groups and consistent group differences across data source were counted.

Disorder prevalence and service contact estimates were significantly higher in survey data in all cases, except for mood disorder. Ratios of survey data to administrative data-based prevalence varied, ranging from 0.80 (mood) to 11.01 (attention-deficit/hyperactivity disorder). Specificity was high (0.98–1.00), sensitivity was low (0.07–0.41) and agreement ranged from slight (κ = 0.13) to moderate (κ = 0.46). Out of 18 sub-group difference comparisons, half were non-significant in either data source. In the remaining nine comparisons, the only significant differences between groups that were consistent across data source were for sex-based differences (attention-deficit/hyperactivity disorder and service contacts). There were no consistent age- or geography-based differences in prevalence across data sources.

Our findings suggest that conclusions drawn about prevalence, service contacts and sub-group differences in these estimates are dependent on data source. Further research is needed to understand who and what is being captured by each source. Researchers should conduct data linkage where possible to access and compare multiple sources of information.

The Passive Surveillance Stroke Severity (PaSSV) Indicator was derived to estimate stroke severity from variables in administrative datasets but has not been externally validated.

We used linked administrative datasets to identify patients with first hospitalization for acute stroke between 2007-2018 in Alberta, Canada. We used the PaSSV indicator to estimate stroke severity. We used Cox proportional hazard models and evaluated the change in hazard ratios and model discrimination for 30-day and 1-year case fatality with and without PaSSV. Similar comparisons were made for 90-day home time thresholds using logistic regression. We also linked with a clinical registry to obtain National Institutes of Health Stroke Scale (NIHSS) and compared estimates from models without stroke severity, with PaSSV, and with NIHSS.

There were 28,672 patients with acute stroke in the full sample. In comparison to no stroke severity, addition of PaSSV to the 30-day case fatality models resulted in improvement in model discrimination (C-statistic 0.72 [95%CI 0.71–0.73] to 0.80 [0.79–0.80]). After adjustment for PaSSV, admission to a comprehensive stroke center was associated with lower 30-day case fatality (adjusted hazard ratio changed from 1.03 [0.96–1.10] to 0.72 [0.67–0.77]). In the registry sample (N = 1328), model discrimination for 30-day case fatality improved with the inclusion of stroke severity. Results were similar for 1-year case fatality and home time outcomes.

Addition of PaSSV improved model discrimination for case fatality and home time outcomes. The validity of PASSV in two Canadian provinces suggests that it is a useful tool for baseline risk adjustment in acute stroke.

Little is known about mental health problems of children and young people (CYP) involved with public and private law family court proceedings, and how these CYP fare compared to those not involved in these significant disruptions to family life.

This study examined records of depression/anxiety in CYP involved in public and private law proceedings using linked population-level data across Wales.

Retrospective e-cohort study. We calculated the incidence of primary-care-recorded depression/anxiety among CYP involved in these proceedings and in a comparison group, using Poisson regression. Depression/anxiety outcomes following proceedings were evaluated using pairwise Cox regression, with age- and gender-matched controls of CYP who had no involvement with the courts.

CYP in the public group had twice the risk of depression (adjusted incidence rate ratio aIRR = 2.2; 95% CI 1.9–2.6) and 20% higher risk of anxiety (aIRR = 1.2; 95% CI 1.0–1.5) relative to the comparison group. The private group had 60% higher risk of depression (aIRR = 1.6; 95% CI 1.4–1.7) and 30% higher risk of anxiety (aIRR = 1.3; 95% CI 1.2–1.4). Following private law proceedings, CYP were more likely to have depression (hazard ratio HR = 1.9; 95% CI 1.7–2.1), and anxiety (HR = 1.4; 95% CI 1.2–1.6) than the control group. Following public proceedings, CYP were more likely to have depression (HR = 2.1; 95% CI 1.7–2.5). Incidence of anxiety or depression following court proceedings was around 4%.

Findings highlight the vulnerability of CYP involved in family court proceedings and increased risk of depression and anxiety. Schools, health professionals, social and family support workers have a role to play in identifying needs and ensuring CYP receive appropriate support before, during and after proceedings.

Schools are a potential stressor for adolescents and may contribute to emergency hospital admissions.

We describe rates of stress-related presentations (SRPs) among school-aged adolescents (11–17 years) during school terms and holidays, and explore differences by age and gender.

Using national administrative hospital data, we defined an SRP as an emergency hospital admission with a primary diagnosis related to pain, psychosomatic symptoms (e.g. fatigue) or mental health problems, or with self-harm indicated in any diagnostic position. We estimated incidence rate ratios for weekly SRPs in term time versus holidays from 2014–2015 to 2017–2018, using negative binomial regression models, stratified by age and gender. We estimated the cumulative incidence of any SRP between 11 and 17 years by analysing prior hospital admission histories of adolescents with an SRP in 2017–2018.

Over the 4-year study period, 305 491 SRPs in 171 013 school-aged adolescents accounted for 31% of emergency admissions for this group. SRPs were predominantly for mental health problems or self-harm (38%), or pain (35%). Weekly admission rates for SRPs were higher in term time than holidays for all ages (age-specific incidence rate ratios were 1.15–1.49 for girls and 1.08–1.60 for boys). Rates were highest for girls aged 14 and 15 years. The estimated cumulative incidence of any SRP between 11 and 17 years was 7.9% for girls and 4.1% for boys.

Hospital admissions for SRPs are common among adolescents, affecting around two girls and one boy in every classroom. Higher rates in term time than holidays suggest that school factors may contribute.