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People with physical diseases are reported to be at elevated risk of subsequent mental disorders. However, previous studies have considered only a few pairs of conditions, or have reported only relative risks. This study aimed to systematically explore the associations between physical diseases and subsequent mental disorders. It examined a population-based cohort of 7,673,978 people living in Denmark between 2000 and 2021, and followed them for a total of 119.3 million person-years. The study assessed nine broad categories of physical diseases (cardiovascular, endocrine, respiratory, gastrointestinal, urogenital, musculoskeletal, hematological and neurological diseases, and cancers), encompassing 31 specific diseases, and the subsequent risk of mental disorder diagnoses, encompassing the ten ICD-10 groupings (organic, including symptomatic, mental disorders; mental disorders due to psychoactive substance use; schizophrenia and related disorders; mood disorders; neurotic, stress-related and somatoform disorders; eating disorders; personality disorders; intellectual disabilities; pervasive developmental disorders; and behavioral and emotional disorders with onset usually occurring in childhood and adolescence). Using Poisson regression, the overall and time-dependent incidence rate ratios (IRRs) for pairs of physical diseases and mental disorders were calculated, adjusting for age, sex and calendar time. Absolute risks were estimated with the Aalen-Johansen estimator. In total, 646,171 people (8.4%) were identified as having any mental disorder during follow-up. All physical diseases except cancers were associated with an elevated risk of any mental disorder. For the nine broad pairs of physical diseases and mental disorders, the median point estimate of IRR was 1.51 (range: 0.99-1.84; interquartile range: 1.29-1.59). The IRRs ranged from 0.99 (95% CI: 0.98-1.01) after cancers to 1.84 (95% CI: 1.83-1.85) after musculoskeletal diseases. Risks varied over time after the diagnosis of physical diseases. The cumulative mental disorder incidence within 15 years after diagnosis of a physical disease varied from 3.73% (95% CI: 3.67-3.80) for cancers to 10.19% (95% CI: 10.13-10.25) for respiratory diseases. These data document that most physical diseases are associated with an elevated risk of subsequent mental disorders. Clinicians treating physical diseases should constantly be alert to the possible development of secondary mental disorders.

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OBJECTIVE: To examine the combined impact of migraine and gestational diabetes mellitus (GDM) on the risks of premature (persons aged ≤60 years) major adverse cardiovascular and cerebrovascular events (MACCE) based on a composite endpoint of fatal and non-fatal myocardial infarction (MI) and stroke. BACKGROUND: Migraine and GDM are risk factors for cardiovascular disease. It is unknown how the combination of migraine and GDM may affect cardiovascular disease risk. METHODS: In a Danish population-based cohort longitudinal study, we established four cohorts among women with at least one pregnancy during 1996-2018: women with migraine, women with GDM, women with both migraine and GDM, and women free of migraine and free of GDM. Risks of premature MACCE and component endpoints were assessed for each cohort. RESULTS: We included 1,307,456 women free of migraine and free of GDM, 56,811 women with migraine, 24,700 women with GDM, and 1484 women with migraine and GDM. The 20-year absolute risk of MACCE was 1.3% (MI: 0.4%, ischemic stroke: 0.6%, hemorrhagic stroke: 0.3%) among women free of migraine and free of GDM, 2.3% (MI: 0.8%, ischemic stroke: 1.2%, hemorrhagic stroke: 0.5%) among women with migraine, 2.2% (MI: 1.0%, ischemic stroke: 1.0%, hemorrhagic stroke: 0.4%) among women with GDM, and 3.7% (MI: 1.7%, ischemic stroke: 1.7%, hemorrhagic stroke: 0.3%) among women with both migraine and GDM. The 20-year adjusted hazard ratio of premature MACCE was 1.65 (95% confidence interval [CI] 1.49-1.82) for women with migraine; 1.64 (95% CI 1.37-1.96) for women with GDM; and 2.35 (95% CI 1.03-5.36) for women with both GDM and migraine when compared with women free of migraine and free of GDM. CONCLUSIONS: Migraine and GDM were each independently associated with an increased risk of MACCE. Risk of premature MACCE was greatest among women with both migraine and GDM, although this risk estimate was imprecise.

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AIM: Patients experiencing cardiac arrest are often burdened with comorbidities that increase mortality. This study examined the impact of comorbidity burden on cardiac arrest mortality by quantifying biological interaction. METHODS: Nationwide population-based Danish cohort study of adult patients hospitalized for cardiac arrest during 1996-2021 and 5:1 matched comparisons from the general population (matched on age, sex, calendar year, and all Charlson Comorbidity Index comorbidities). Mortality rates and hazard ratios for the association between cardiac arrest and mortality was calculated according to comorbidity burden (none, low, moderate, severe). Biological interaction was examined by calculating interaction contrasts (difference in rate differences). RESULTS: For no comorbidity burden, the 30-day mortality rate per 1,000 person-years was 18,110 in the cardiac arrest cohort and 24 in the comparison cohort (hazard ratio = 1,435). For low comorbidity burden, the 30-day mortality rate increased to 20,272 in the cardiac arrest cohort and 41 in the comparison cohort (hazard ratio = 504). The corresponding interaction contrast of 2,145 indicated that 11% of the mortality rate in patients with cardiac arrest and low comorbidity burden was explained by interaction between the two. This percentage increased to 20% for moderate and to 28% for severe comorbidity burden. Within 31-365-day follow-up, the percentage of the mortality rate explained by interaction was 28% for low, 38% for moderate, and 41% for severe comorbidity burden. The interaction effect was present for both out-of-hospital and in-hospital cardiac arrest. CONCLUSIONS: Comorbidity burden interacted with cardiac arrest to increase mortality beyond that explained by their separate effects.

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Patient characteristics and platelet responses at romiplostim initiation according to the duration of immune thrombocytopenia (ITP) are poorly understood. Amongst romiplostim-exposed adults with ITP lasting ≥6 months during 2009-2018 in Denmark, Sweden, and Norway, we examined characteristics at romiplostim initiation, romiplostim dosage, and durable platelet response (≥75% of measurements ≥50 × 109/L at 14-24 weeks) for subcohorts with newly diagnosed (duration <3 months), persistent (3-12 months), or chronic (>12 months) ITP initiating romiplostim. The 285 romiplostim initiators comprised 81 (28%) with newly diagnosed, 47 (16%) with persistent, and 157 (55%) with chronic ITP. More patients with newly diagnosed ITP than longer ITP duration, had low comorbidity levels, two or more prior ITP therapies, and previous bleeding requiring hospitalisation. The median romiplostim doses were similar across subcohorts. During treatment, median platelet counts were similar across subcohorts (75-76 × 109/L), and the durable platelet response was 64.6%, 52.9%, and 52.7% for newly diagnosed, persistent, and chronic ITP, respectively. After treatment cessation, the median platelet count was 138 × 109/L, 68 × 109/L, and 71 × 109/L, respectively. In conclusion, newly diagnosed patients, compared with romiplostim initiators with longer disease duration, had more severe ITP, higher frequency of durable platelet response, and higher median platelet count after cessation.

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BACKGROUND: The use of fertility indicators to predict ovulation has largely been studied for contraceptive purposes, while less so as fertility-promoting tools. OBJECTIVE: To investigate the association between fertility indicators and fecundability in Danish women trying to conceive. METHODS: Web-based preconception cohort study. We analysed data from 11,328 females aged 18-49 years trying to conceive without fertility treatment for ≤6 menstrual cycles, from the Danish SnartGravid.dk and SnartForældre.dk cohorts (2007-2023). Participants reported the use of fertility indicators (counting days since the last menstrual period, cervical fluid monitoring, urinary ovulation testing, feeling ovulation, using a smartphone fertility app and measuring basal body temperature [BBT]). Time to pregnancy was measured in menstrual cycles ascertained by self-reported pregnancy status. We estimated fecundability ratios (FR) and 95% confidence intervals (CIs) using proportional probabilities regression models adjusted for age, socio-economic position, health indicators, reproductive history and gynaecological factors. RESULTS: Fertility indicators were used by 63.3% of participants at study entry. Counting days was the most common (46.9%), while measuring BBT was the least (3.0%). Other indicators ranged from 17.0% to 23.6%, with 69.7% using more than one indicator. Compared with non-use, use of any fertility indicator was associated with greater fecundability (adjusted FR 1.14, 95% CI 1.08, 1.19). Cervical fluid monitoring showed the strongest association (aFR 1.46, 95% CI 1.03, 2.07), followed by urinary ovulation testing (aFR 1.35, 95% CI 1.16, 1.58) and counting days (aFR 1.18, 95% CI 1.09, 1.29). Feeling ovulation and fertility apps were modestly associated with fecundability, while measuring BBT was not associated. Sensitivity analysis restricting to ≤2 cycles of attempt time and two cycles of follow-up showed an aFR for any indicator use of 1.21 (95% CI 1.13, 1.31). CONCLUSION: In this Danish preconception cohort, use of fertility indicators was associated with a higher fecundability, varying by type of indicator.

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BACKGROUND: To examine whether obstructive uropathy is associated with increased risk of cancer and whether mortality differs between patients with cancer with and without obstructive uropathy. METHODS: In a nationwide population-based Danish cohort study including 37,275 adult patients with a first-time hospital-related diagnosis of obstructive uropathy in 1996 to 2022, we assessed cumulative cancer incidence (risk) and standardized incidence ratios (SIR). Furthermore, we compared the mortality of 7,485 patients diagnosed with cancer after obstructive uropathy diagnosis with that of 69,785 patients with cancer without obstructive uropathy matched by age, sex, cancer site, stage, and calendar year of cancer diagnosis. RESULTS: The 3-month risk of cancer after an obstructive uropathy diagnosis was 9.6%. The 3-month SIR was 34.2 [95% confidence interval (CI), 33.1-35.4] while the 1 to <5 year SIR was 1.2 (95% CI, 1.1-1.3). The 3-month SIRs were 82.7 (95% CI, 79.3-86.2) for urological cancer, 88.8 (95% CI, 79.8-98.5) for gynecological cancer, and 13.9 (95% CI, 12.0-15.9) for colorectal cancer. After 1 year of follow-up, the excess number of urological cancers decreased to 0.1 per 100 person-years, whereas we observed no excess risk of gynecological and colorectal cancers. The 5-year all-cause mortality following cancer was 64.1% (95% CI, 62.9-65.2) in patients with an obstructive uropathy diagnosis before cancer diagnosis and 53.2% (95% CI, 52.9-53.6) in those without. CONCLUSIONS: A first-time diagnosis of obstructive uropathy can be a clinical marker of underlying undiagnosed cancer and elevated mortality in relation to any cancer diagnosed after obstructive uropathy. IMPACT: These findings can inform the follow-up recommendations for obstructive uropathy.

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OBJECTIVE: To compare stillbirth rates and risks for small for gestational age (SGA), large for gestational age (LGA) and appropriate for gestational age (AGA) pregnancies at 24-44 completed weeks of gestation using a birth-based and fetuses-at-risk approachs. DESIGN: Population-based, multi-country study. SETTING: National data systems in 15 high- and middle-income countries. POPULATION: Live births and stillbirths. METHODS: A total of 151 country-years of data, including 126 543 070 births across 15 countries from 2000 to 2020, were compiled. Births were categorised into SGA, AGA and LGA using INTERGROWTH-21st standards. Gestation-specific stillbirth rates, with total births as the denominator, and gestation-specific stillbirth risks, with fetuses still in utero as the denominator, were calculated from 24 to 44 weeks of gestation. MAIN OUTCOME MEASURES: Gestation-specific stillbirth rates and risks according to size at birth. RESULTS: The overall stillbirth rate was 4.22 per 1000 total births (95% CI 4.22-4.23) across all gestations. Applying the birth-based approach, the stillbirth rates were highest at 24 weeks of gestation, with 621.6 per 1000 total births (95% CI 620.9-622.2) for SGA pregnancies, 298.4 per 1000 total births (95% CI 298.1-298.7) for AGA pregnancies and 338.5 per 1000 total births (95% CI 337.9-339.0) for LGA pregnancies. Applying the fetuses-at-risk approach, the gestation-specific stillbirth risk was highest for SGA pregnancies (1.3-1.4 per 1000 fetuses at risk) prior to 29 weeks of gestation. The risk remained stable between 30 and 34 weeks of gestation, and then increased gradually from 35 weeks of gestation to the highest rate of 8.4 per 1000 fetuses at risk (95% CI 8.3-8.4) at ≥42 weeks of gestation. The stillbirth risk ratio (RR) was consistently high for SGA compared with AGA pregnancies, with the highest RR observed at ≥42 weeks of gestation (RR 9.2, 95% CI 15.2-13.2), and with the lowest RR observed at 24 weeks of gestation (RR 3.1, 95% CI 1.9-4.3). The stillbirth RR was also consistently high for SGA compared with AGA pregnancies across all countries, with national variability ranging from RR 0.70 (95% CI 0.43-0.97) in Mexico to RR 8.6 (95% CI 8.1-9.1) in Uruguay. No increased risk for LGA pregnancies was observed. CONCLUSIONS: Small for gestational age (SGA) was strongly associated with stillbirth risk in this study based on high-quality data from high- and middle-income countries. The highest RRs were seen in preterm gestations, with two-thirds of the stillbirths born as preterm births. To advance our understanding of stillbirth, further analyses should be conducted using high-quality data sets from low-income settings, particularly those with relatively high rates of SGA.

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Background: Observational studies of SARS-CoV-2 vaccine effectiveness are prone to confounding, which can be illustrated using negative control methods. Methods: Nationwide population-based cohort study including two cohorts of Danish residents 60-90 years of age matched 1:1 on age and sex: A vaccinated and a non-vaccinated cohort, including 61052 SARS-CoV-2 vaccinated individuals between 1 March and 1 July 2021 and 61052 individuals not vaccinated preceding 1 July 2021. From these two cohorts, we constructed negative control cohorts of individuals diagnosed with SARS-CoV-2 infection or acute myocardial infarction, stroke, cancer, low energy fracture, or head-trauma. Outcomes were SARS-CoV-2 infection, negative control outcomes (eg, mammography, prostate biopsy, operation for cataract, malignant melanoma, examination of eye and ear), and death. We used Cox regression to calculate adjusted incidence and mortality rate ratios (aIRR and aMRR). Results: Risks of SARS-CoV2 infection and all negative control outcomes were elevated in the vaccinated population, ranging from an aIRR of 1.15 (95% CI: 1.09-1.21) for eye examinations to 3.05 (95% CI: 2.24-4.14) for malignant melanoma. Conversely, the risk of death in the SARS-CoV-2 infected cohort and in all negative control cohorts was lower in vaccinated individuals, ranging from an aMRR of 0.23 (95% CI: 0.19-0.26) after SARS-CoV-2 infection to 0.50 (95% CI: 0.37-0.67) after stroke. Conclusion: Our findings indicate that observational studies of SARS-CoV-2 vaccine effectiveness may be subject to substantial confounding. Therefore, randomized trials are essential to establish vaccine efficacy after the emergence of new SARS-CoV-2 variants and the rollout of multiple booster vaccines.

Why was this study done: : After the emergence of new SARS-CoV-2 variants and the rollout of multiple booster SARS-CoV-2 vaccines, the impact of vaccination on risk of SARS-CoV-2 infection and death after the infection has mainly been explored in observational studies. We used negative control methods to investigate whether confounding affects the results of observational SARS-CoV-2 vaccine effectiveness studies. Findings: : We used Danish registry data obtained during the SARS-CoV-2 vaccine roll-out to conduct a nationwide, matched population-based cohort study of Danish residents 60­90 years in which we compared vaccinated individuals with non-vaccinated individuals. Compared with unvaccinated individuals, vaccinated individuals had increased risks of SARS-CoV2 infection but also had increased risks of all negative control outcomes (mammography, prostate biopsy, operation for cataract, malignant melanoma, examination of eye and ear). The risk of death after SARS-CoV2 infection was lower in the vaccinated cohort, as was the risk of death after acute myocardial infarction, stroke, cancer, low energy fracture, and head-trauma. Meaning: : The negative control methods indicate that observational studies of SARS-CoV-2 vaccine effectiveness may be prone to substantial confounding which may impact the observed associations. This bias may both lead to underestimation of vaccine effectiveness (increased risk of SARS-CoV2 infection among vaccinated individuals) and overestimation of the vaccine effectiveness (decreased risk of death after of SARS-CoV2 infection among vaccinated individuals). Our results highlight the need for randomized vaccine efficacy studies after the emergence of new SARS-CoV-2 variants and the rollout of multiple booster vaccines.

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BACKGROUND: Urticaria has been tentatively linked to cancer, but epidemiological evidence supporting this link is sparse and conflicting. We therefore conducted a population-based cohort study using healthcare databases of the Danish population (January 1980-December 2022). We followed 87,507 people for a median of 10.1 years after first hospital contact for urticaria. OBJECTIVES: To examine associations of a hospital diagnosis of urticaria with incident cancer. METHODS: We computed absolute risk of cancer and standardized incidence ratios (SIRs) with 95% confidence intervals (CIs) standardized to Danish national cancer rates. In a cross-sectional analysis, we examined whether the extent of cancer spread differed between people with vs. without a previous urticaria diagnosis. RESULTS: The overall SIR for all types of cancer was 1.09 (95% CI, 1.06-1.11) based on 7,788 observed vs. 7,161 expected cases. The risk for any cancer was 0.7% (95% CI, 0.6-0.7) for the first year of follow-up. Cancer was diagnosed in 588 people with urticaria during the first year of follow-up (SIR 1.49, 95% CI, 1.38-1.62) and in 7,200 people thereafter (SIR 1.06, 95% CI, 1.04-1.09). During the first year of follow-up, we found strong associations with hematological cancers (e.g., non-Hodgkin lymphoma SIR 2.91, 95% CI, 1.92-4.23). Cancer stage was similar in people with vs. without previous urticaria diagnosis. CONCLUSIONS: At the time of urticaria diagnosis, or in the first year afterwards, we found a large increase in the risk for cancer. In subsequent years, a persistent 6% increase in risk remained. Diagnostic efforts may partly explain the elevated short-term risk, but occult cancer may promote urticaria, or cancer and urticaria share common risk factors.

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BACKGROUND: Some autoimmune diseases carry elevated risk for atherosclerotic cardiovascular disease (ASCVD), yet the underlying mechanism and the influence of traditional risk factors remain unclear. OBJECTIVES: This study sought to determine whether autoimmune diseases independently correlate with coronary atherosclerosis and ASCVD risk and whether traditional cardiovascular risk factors modulate the risk. METHODS: The study included 85,512 patients from the Western Denmark Heart Registry undergoing coronary computed tomography angiography. A diagnosis of 1 of 18 autoimmune diseases was assessed. Adjusted OR (aOR) for any plaque, any coronary artery calcification (CAC), CAC of >90th percentile, and obstructive coronary artery disease as well as adjusted HR (aHR) for ASCVD were calculated. RESULTS: During 5.3 years (Q1-Q3: 2.8-8.2 years) of follow-up, 3,832 ASCVD events occurred. A total of 4,064 patients had a diagnosis of autoimmune disease, which was associated with both presence of any plaque (aOR: 1.29; 95% CI: 1.20-1.40), any CAC (aOR: 1.28; 95% CI: 1.19-1.37), and severe CAC of >90th percentile (aOR: 1.53; 95% CI: 1.39-1.68), but not with having obstructive coronary artery disease (aOR: 1.04; 95% CI: 0.91-1.17). Patients with autoimmune diseases had a 46% higher risk (aHR: 1.46; 95% CI: 1.29-1.65) for ASCVD. Traditional cardiovascular risk factors were strongly associated with future ASCVD events, and a favorable cardiovascular risk factor profile in autoimmune patients was associated with ∼54% lower risk compared to patients with presence of risk factors (aHR: 0.46; 95% CI: 0.27-0.81). CONCLUSIONS: Autoimmune diseases were independently associated with higher burden of coronary atherosclerosis and higher risk for future ASCVD events, with risk accentuated by traditional cardiovascular risk factors. These findings suggest that autoimmune diseases increase risk through accelerated atherogenesis and that cardiovascular risk factor control is key for improving prognosis in patients with autoimmune diseases.

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INTRODUCTION: The prognosis for stroke patients with type 2 diabetes mellitus (T2DM) remains poorly understood. We examined the risk of mortality and stroke recurrence in stroke patients with T2DM and stroke patients without diabetes. PATIENTS AND METHODS: We conducted a population-based cohort study including all patients diagnosed with a first-time ischemic stroke (n = 131,594) or intracerebral hemorrhage (ICH, n = 15,492) in Denmark, 2005-2021. Patients with T2DM were identified using hospital diagnosis codes and glucose-lowering drug prescriptions. We calculated risks, risk differences, and risk ratios, standardized by age, sex, and calendar year of stroke admission. RESULTS: Following ischemic stroke, the 5-year standardized mortality was 46.1% for patients with T2DM and 35.4% for patients without diabetes (standardized risk difference: 10.7% [95% CI 9.9-11.6]; risk ratio: 1.3 [95% CI 1.3-1.3]). The 5-year risk of recurrence following ischemic stroke was 12.7% for patients with T2DM and 11.3% for those without diabetes (risk difference: 1.4% [95% CI 0.9-2.0]; risk ratio: 1.1 [95% CI 1.1-1.2]). Following ICH, the 5-year mortality was 62.8% for patients with T2DM and 53.0% for patients without diabetes (risk difference: 9.8% [95% CI 7.2-12.4)]; risk ratio: 1.2 [95% CI 1.1-1.2]). The 5-year risk of recurrence after ICH was 9.1% for patients with T2DM and 9.7% for patients without diabetes. DISCUSSION AND CONCLUSION: Stroke patients with T2DM were at increased risk of mortality. The risk of stroke recurrence was slightly higher for ischemic stroke patients with T2DM than patients without diabetes, while no difference was observed among ICH patients.

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BACKGROUND: Gestational diabetes is associated with adverse outcomes such as preterm birth (<37 weeks). However, there is no international consensus on screening criteria or diagnostic levels for gestational diabetes, and it is unknown whether body mass index (BMI) or obesity modifies the relation between glucose level and preterm birth. METHODS: We studied a pregnancy cohort restricted to two Danish regions from the linked Danish Medical Birth Register to study associations between glucose measurements from the 2-hour postload 75-g oral glucose tolerance test (one-step approach) and preterm birth from 2004 to 2018. In Denmark, gestational diabetes screening is a targeted strategy for mothers with identified risk factors. We used Poisson regression to estimate rate ratios (RR) of preterm birth with z-standardized glucose measurements. We assessed effect measure modification by stratifying analyses and testing for heterogeneity. RESULTS: Among 11,337 pregnancies (6.2% delivered preterm), we observed an adjusted preterm birth RR of 1.2 (95% confidence interval [CI] = 1.1, 1.3) for a one-standard deviation glucose increase of 1.4 mmol/l from the mean of 6.7 mmol/l. There was evidence for effect measure modification by obesity, for example, adjusted RR for nonobese (BMI, <30): 1.2 (95% CI = 1.1, 1.3) versus obese (BMI, ≥30): 1.3 (95% CI = 1.2-1.5), P = 0.05 for heterogeneity. CONCLUSION: Among mothers screened for gestational diabetes, increased glucose levels, even those below the diagnostic level for gestational diabetes in Denmark, were associated with increased preterm birth risk. Obesity (BMI, ≥30) may be an effect measure modifier, not just a confounder, of the relation between blood glucose and preterm birth risk.

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PURPOSE: Comorbidity level is a predictor of infection in the first 30 days after hip fracture surgery. However, the roles of individual comorbid diseases as predictors of infection remain unclear. We investigated individual major comorbid diseases as predictors of infection after hip fracture surgery. METHODS: We obtained Danish population-based medical registry data for patients undergoing hip fracture surgery (2004-2018). Information was obtained on 27 comorbidities, included in various comorbidity indices, 5 years before surgery. The primary outcome was any hospital-treated infection within 30 days after surgery. Cumulative incidence of infection was calculated by considering death as competing risk. We used logistic regression to compute mutually adjusted odds ratios with 95% confidence interval for infection. RESULTS: Of 92,239 patients with hip fracture, 71% were women, and the median age was 83 years. The most prevalent comorbidities were hypertension (23%), heart arrhythmia (15%), and cerebrovascular disease (14%). The 30-day incidence of infection was 15% and 12% among the total cohort and among patients with no record of comorbidities, respectively. Infection incidence was highest among patients with renal disease (24%), depression/anxiety (23%), and chronic pulmonary disease (23%), and lowest among patients with metastatic solid tumor (15%). Adjusted odds ratios of infection ranged from 0.94 [0.80-1.10] for metastatic solid tumor to 1.77 [1.63-1.92] for renal disease. CONCLUSION: Most comorbid diseases were predictors of infection after surgery for hip fracture. Awareness of patients' comorbidity profiles might help clinicians initiate preventive measures or inform patients of their expected risk.

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INTRODUCTION: Based on technical advancements and clinical evidence, transcatheter aortic valve implantation (TAVI) has been widely adopted. New generation TAVI valve platforms are continually being developed. Ideally, new valves should be superior or at least non-inferior regarding efficacy and safety, when compared to best-in-practice contemporary TAVI valves. METHODS AND ANALYSIS: The Compare-TAVI trial (ClinicalTrials.gov NCT04443023) was launched in 2020, to perform a 1:1 randomized comparison of new vs contemporary TAVI valves, preferably in all comers. Consecutive cohorts will be launched with sample sizes depending on the choice of interim analyses, expected event rates, and chosen superiority or non-inferiority margins. Enrollment has just been finalized in cohort B, comparing the Sapien 3/Sapien 3 Ultra Transcatheter Heart Valve (THV) series (Edwards Lifesciences, Irvine, California, USA) and the Myval/Myval Octacor THV series (Meril Life Sciences Pvt. Ltd., Vapi, Gujarat, India) balloon expandable valves. This non-inferiority study was aimed to include 1062 patients. The 1-year composite safety and efficacy endpoint comprises death, stroke, moderate-severe aortic regurgitation, and moderate-severe valve deterioration. Patients will be followed until withdrawal of consent, death, or completion of 10-year follow-up, whichever comes first. Secondary endpoints will be monitored at 30 days, 1, 3, 5, and 10 years. SUMMARY: The Compare-TAVI organization will launch consecutive cohorts wherein patients scheduled for TAVI are randomized to one of two valves. The aim is to ensure that the short- and long-term performance and safety of new valves being introduced is benchmarked against what achieved by best-in-practice contemporary valves.

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Clinicians, researchers, regulators, and other decision-makers increasingly rely on evidence from real-world data (RWD), including data routinely accumulating in health and administrative databases. RWD studies often rely on algorithms to operationalize variable definitions. An algorithm is a combination of codes or concepts used to identify persons with a specific health condition or characteristic. Establishing the validity of algorithms is a prerequisite for generating valid study findings that can ultimately inform evidence-based health care. This paper aims to systematize terminology, methods, and practical considerations relevant to the conduct of validation studies of RWD-based algorithms. We discuss measures of algorithm accuracy; gold/reference standard; study size; prioritizing accuracy measures; algorithm portability; and implication for interpretation. Information bias is common in epidemiologic studies, underscoring the importance of transparency in decisions regarding choice and prioritizing measures of algorithm validity. The validity of an algorithm should be judged in the context of a data source, and one size does not fit all. Prioritizing validity measures within a given data source depends on the role of a given variable in the analysis (eligibility criterion, exposure, outcome or covariate). Validation work should be part of routine maintenance of RWD sources.

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Purpose: In the Danish National Patient Registry (DNPR), covering all Danish hospitals and widely used in research, diseases have been recorded using International Classification of Diseases (ICD) codes, transitioning from the Eighth to the Tenth revision in 1994. Uncertainty exists regarding whether including ICD-8 codes alongside ICD-10 is needed for complete disease identification. We assessed the extent of left-truncation and left-censoring in the DNPR arising from omitting ICD-8 codes. Patients and Methods: We sampled 500,000 Danes ≥40 years of age in 1995, 2010, and 2018. From the DNPR, we identified cardiovascular, endocrine, gastrointestinal, neurological, pulmonary, rheumatic, and urogenital diseases as well as fractures. We obtained the number of people with a disease recorded with ICD-8 codes only (ie, the ICD-8 record would be left-truncated by not using ICD-8 codes), ICD-8 plus ICD-10 codes (ie, the ICD-8 record would be left-censored by not using ICD-8 codes), and ICD-10 codes only. For each ICD group, we calculated the proportion of people with the disease relative to the total sample (ie, 500,000 people) and the total number of people with the disease across all ICD groups. Results: Overall, the left-truncation issue decreased over the years. Relative to all people with a disease, the left-truncated proportion was for example 59% in 1995 and <2% in 2018 for diabetes mellitus; 93% in 1995, and 54% in 2018 for appendicitis. The left-truncation issue increased with age group for most diseases. The proportion of disease records left-censored by not using ICD-8 codes was generally low but highest for chronic diseases. Conclusion: The left-truncation issue diminished over sample years, particularly for chronic diseases, yet remained rather high for selected surgical diseases. The left-truncation issue increased with age group for most diseases. Left-censoring was overall a minor issue that primarily concerned chronic diseases.

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AIMS: To examine the longitudinal heterogeneity of HbA1c preceding the initiation of diabetes treatment in clinical practice. METHODS: In this population-based study, we used HbA1c from routine laboratory and healthcare databases. Latent class trajectory analysis was used to classify individuals according to their longitudinal HbA1c patterns before first glucose-lowering drug prescription irrespective of type of diabetes. RESULTS: Among 21,556 individuals initiating diabetes treatment during 2017-2018, 20,733 (96 %) had HbA1c measured (median 4 measurements [IQR 2-7]) in the 5 years preceding treatment initiation. Four classes with distinct HbA1c trajectories were identified, with varying steepness of increase in HbA1c. The largest class (74 % of the individuals) had mean HbA1c above the 48 mmol/mol threshold 9 months before treatment initiation. Mean HbA1c was 52 mmol/mol (95 % CI 52-52) at treatment initiation. In the remaining three classes, mean HbA1c exceeded 48 mmol/mol almost 1.5 years before treatment initiation and reached 79 mmol/mol (95 % CI 78-80), 105 mmol/mol (95 % CI 104-106), and 137 mmol/mol (95 % CI 135-140) before treatment initiation. CONCLUSION: We identified four distinct longitudinal HbA1c patterns before initiation of diabetes treatment in clinical practice. All had mean HbA1c levels exceeding the diagnostic threshold many months before treatment initiation, indicating therapeutic inertia.

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BACKGROUND AND PURPOSE: Revisions due to periprosthetic joint infection (PJI) are underestimated in national arthroplasty registries. Our primary objective was to assess the validity in the Danish Knee Arthroplasty Register (DKR) of revisions performed due to PJI against the Healthcare-Associated Infections Database (HAIBA). The secondary aim was to describe the cumulative incidences of revision due to PJI within 1 year of primary total knee arthroplasty (TKA) according to the DKR, HAIBA, and DKR/HAIBA combined. METHODS: This longitudinal observational cohort study included 56,305 primary TKAs (2010-2018), reported in both the DKR and HAIBA. In the DKR, revision performed due to PJI was based on pre- and intraoperative assessment disclosed by the surgeon immediately after surgery. In HAIBA, PJI was identified from knee-related revision procedures coinciding with 2 biopsies with identical microbiological pathogens. We calculated the sensitivity, specificity, positive predictive value (PPV), and negative predictive value (NPV) of revision due to PJI in the DKR (vs. HAIBA, within 1 year of TKA) with 95% confidence intervals (CI). Cumulative incidences were calculated using the Kaplan-Meier method. RESULTS: The DKR's sensitivity for PJI revision was 58% (CI 53-62) and varied by TKA year (41%-68%) and prosthetic type (31% for monoblock; 63% for modular). The specificity was 99.8% (CI 99.7-99.8), PPV 64% (CI 62-72), and NPV 99.6% (CI 99.6-99.7). 80% of PJI cases not captured by the DKR were caused by non-reporting rather than misclassification. 33% of PJI cases in the DKR or HAIBA were culture-negative. Considering potential misclassifications, the best-case sensitivity was 64%. The cumulative incidences of PJI were 0.8% in the DKR, 0.9% in HAIBA, and 1.1% when combining data. CONCLUSION: The sensitivity of revision due to PJI in the DKR was 58%. The cumulative incidence of PJI within 1 year after TKA was highest (1.1%) when combining the DKR and HAIBA, showing that incorporating microbiology data into arthroplasty registries can enhance PJI validity.

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Aim: To examine whether low-density lipoprotein cholesterol (LDL-C) levels influence the cardiovascular risk associated with non-aspirin non-steroidal anti-inflammatory drug (NSAID) use after myocardial infarction (MI). Methods: Using Danish health registries, we conducted a population-based cohort study of all adult patients with first-time MI during 2010-2020 with an LDL-C value before discharge. Based on the latest LDL-C value, we categorized patients into a low and a high LDL-C group (<3.0 vs ≥3.0 mmol/L). We used time varying Cox regression to compute hazard ratios (HRs) with 95% confidence intervals of the association between NSAID use and a major adverse cardiovascular event (MACE: recurrent MI, ischemic stroke, and all-cause death). Results: We followed 50,573 patients for a median of 3.1 years. While exposed, 521 patients experienced a MACE: 312 in the low LDL-C group and 209 in the high LDL-C group. The HRs for MACE comparing NSAID use with non-use were 1.21 (1.11-1.32) overall, 1.19 (1.06-1.33) in the low LDL-C group, and 1.23 (1.07-1.41) in the high LDL-group. The HRs for recurrent MI and ischemic stroke were comparable between the LDL-C subgroups. The HRs for all-cause death were 1.22 (1.07-1.39) in the low LDL-C group and 1.54 (1.30-1.83) in the high LDL-C group. Changing the cut-off value for LDL-C to 1.8 and 1.4 mmol/L showed consistent results. Conclusion: In patients with MI, LDL-C levels did not influence the increased risk of MACE associated with NSAID use, but might influence the association between NSAID use and all-cause death.