dataesr/scientific-paragraphs-categorization huggingface dataset:
It has been shown that oblique impacts have their own mechanisms and injury patterns  [38] , however this category does not exist in our database. As a consequence, oblique impacts might have been indifferently put in either "frontal" or "lateral" ones. A possible side-effect is that crashes with distinct consequences on the car occupants may have been put together in the same stratum, possibly reducing the between strata heterogeneity and thus artificially increasing the similarity of both frontal and lateral injury patterns. Second, the AIS coding is directly related to the victim's management and based on information available in medical records. Hence, because of the emergency of the management of road accident victims, clinicians might have overlooked minor lesions where more serious ones were present.
This may have undermined the number of associations between severe and mild injuries, while some of them are of high interest, as it was explained earlier with the clavicle fracture. However, this possible bias was mitigated by the fact the coding was performed retrospectively by an ER physician based on the patient medical images and physiological analyses. The study did not consider the most recent cases within the database (after 2014), and the classification used (AIS1990) is not the most recent version of the AIS. This might undermine the direct application of the results of this study for policy-making. However, this choice is due to two main reasons: the Rhône registry used the AIS1990 classification up until 2014, so the wide majority of the database entries are coded using this classification.
Moreover, a direct translation to AIS1990 to more recent versions is not always possible and requires the patient medical records which are not available in the database. So, in order to keep the highest statistical power possible by having the largest number of cases possible, the choice was made to consider the cases before 2014. Finally, the associations were computed only two-bytwo. As shown in Ballout et al. [12] , it is possible to consider interactions between injuries (second, third or higher-order interactions) to take into account the potential associations between three or more different injuries as well. However, the computational burden may rapidly become an issue due to the considerable increase of parameters in the models. Although in the BC we defined groups of injuries based on a priori knowledge (e.
Conclusion The article presented an innovative approach to exploit an epidemiological database of road accident victim injuries. First, injury associations were computed on data stratified by accident type (lateral/frontal impacts). Then, an alternative injury classification was proposed aiming at better highlighting the biomechanics underlying injury associations. Finally, a thorough analysis of these associations was performed which led to the following main conclusions: • The global association patterns are similar in frontal and lateral impact suggesting that most of them are injury-mechanism independent. • Several impact-specific injury associations were found and could be linked to either particular injury mechanisms (e. g. contact with driving wheel) or differences in the human body mechanical properties between antero-posterior and fronto-lateral axes.
Acknowledgements We thank everyone who participated in the data collection and data recording for the  Rhône Road Accident Registry Association  (ARVAC: president,  E. Javouhey ), and University Gustave Eiffel -campus of Lyon -TS2-Umrestte (scientific coordinator,  B. Laumon , medical coordinator,  A. Ndiaye  and administrative coordinator,  B. Gadegbeku ).
Study Variables Demographic information, including age, sex, race, education and employment history, and healthcare coverage, was collected from all respondents. Data also were collected on chronic GVHD characteristics, including overall disease duration, presence of symptoms at the time of the survey, and LSS score (total score range 0 to 100, with higher score indicating more bothersome symptoms)  [15] , severity (mild/moderate or severe), and duration (<6 versus 6 months) of chronic GVHD when symptoms were at their worst.
Demographic, clinical characteristic, and caregiver data were assessed in the full analysis population (ie, all eligible respondents). Data pertaining to employment and income change were assessed in the full analysis population (ie, those who met all eligibility criteria and completed the survey), as well as in the subset of patients who reported full-or parttime employment at the time of the most recent transplantation. Response options for the items pertaining to the extent of reliance on caregivers included "never," "rarely," "sometimes," "often," and "always/all the time," with any selections other than "never" or "rarely" considered to indicate regular assistance for the data analysis.
Statistical Analyses Participants were required to answer all relevant questions for inclusion in our analyses; no missing data were present in the final data set. Survey responses were analyzed overall and stratified by respondent-specified chronic GVHD severity (mild/moderate versus severe) and duration (<6 months versus 6 months). All data were analyzed using SAS version 9. 4 (SAS Institute, Cary, NC) and summarized using descriptive statistics. The noninterventional study design was descriptive in nature and not powered for formal statistical analyses of differences between subgroups. Because the majority of the survey items were intended to be analyzed independently and descriptively, the pilot test for comprehension and comprehensiveness was deemed sufficient for reporting basic descriptions.
Additionally, there was relatively low representation of racial and ethnic minorities, which might limit the generalizability of our findings or potentially underestimate the overall extent of employment and economic hardships faced by patients with chronic GVHD from marginalized groups. Recall bias was possible, as respondents reported their experiences at diagnosis and when symptoms were at their worst. Chronic GVHD diagnoses and clinical characteristics (eg, disease duration and severity) were self-reported by survey respondents and were not confirmed by a physician or medical records review. Furthermore, patient caregivers were not surveyed in this study, so the described impact of chronic GVHD on caregiver employment was based on respondents' reports. Additionally, data pertaining to duration of caregiver assistance were not collected, so the time cost of informal caregiving could not be evaluated.
ACKNOWLEDGMENTS Writing assistance was provided by Jane Kovalevich, PhD, an employee of ICON (Blue Bell, PA), and was funded by Incyte Corporation. Financial disclosure: This study was funded by Incyte Corporation). Conflict of interest statement: J. Y. , V. B. , and J. G. are employees and shareholders of Incyte Corporation. N. K. has served as a consultant for Incyte. J. T. , P. W. , and O. M. are employees of IQVIA, the company commissioned by Incyte to conduct this study. S. K. S. 's not-for-profit employer has received unrestricted educational grants in the past 3 years from Incyte, Kadmon, Syndax, Omeros, and Pharmacyclics. S. J. L. has received research funding from Amgen, AstraZeneca, Incyte, Kadmon, Novartis, Pfizer, Syndax, and Takeda; is a member of a steering committee for Incyte; and has received consulting fees from Mallinckrodt, Equillium, and Kadmon.
Authorship statement: All authors contributed to manuscript preparation and approved the manuscript for submission. J. Y. and N. K. contributed equally to this work. Availability of data and materials: Incyte Corporation is committed to data sharing that advances science and medicine while protecting patient privacy. Qualified external scientific researchers may request anonymized datasets owned by Incyte for the purpose of conducting legitimate scientific research. Researchers may request anonymized datasets from any interventional study (except Phase 1 studies) for which the product and indication have been approved on or after January 1, 2020, in at least one major market (eg. US, EU, Japan). Data will be available for request after the primary publication or 2 years after the study has ended.
Study Population All consecutive adult patients who were weaned off HPN at a tertiary referral center (CHU Beaujon, Clichy, France) between June 2019 and June 2022 were identified from a prospectively maintained database (IRB approval number CER-2021-73). Patients with an IVS duration of >1 month and without chronic infections (e. g. , HIV) or primary malignant causes of HPN were included, which is similar to previous studies  [6, 15]. The development of new malignancies and the use of systemic anti-cancer therapy or death during HPN were recorded. The reasons for weaning off IVS were restoration of continuity (RC) or spontaneous adaptation with standard dietetic and medical treatment  [1]. Since the marketing authorization of teduglutide (TED) in France (October 2015), enhanced adaptation was also possible in SBS patients with ongoing IVS, despite standard treatment  [1].
Data Collection The patient demographics and clinical characteristics were collected from medical records, including the dates of IVS initiation and withdrawal. This also included any previous need for IVS and/or enteral nutrition (EN) or a need to restart IVS during followup (FU). Patients were routinely evaluated every 3 to 6 months during and after weaning off IVS at the outpatient clinic, and data from both the first (start) and the final date of IVS (stop), and the longest available duration of FU, were used. Besides BW and BMI, blood tests included serum albumin levels, creatinine, electrolytes, and C-reactive protein (CRP). Micronutrients (trace elements and vitamins) were measured every 6 months to 1 year and during FU after weaning. As of June 2021, body composition was determined using bioelectrical impedance analysis (BIA) according to the manufacturer's instructions (Bodystat 1500, Bodystat, Douglas, Isle of Man).
Reduced HGS (<16 kg for women and <27 kg for men) and sarcopenia were based on the revised European consensus  [22] , with additional use of age-and gender-specific cut-offs for HGS  [19]. Finally, correlations between the variables of interest were determined using the Spearman correlation coefficient. For all analyses, two-tailed p-value < 0. 05 were considered significant, and 0. 05 < p < 0. 1 were considered a trend. Data were analyzed in Prism GraphPad, version 8. 0 (Graphpad Software, San Diego, CA, USA).
Reagents, DNA, strains Unless otherwise noted, all reagents were purchased from Millipore Sigma, St. Louis, MO. The plasmid encoding sfGFP is pY71-sfGFP (GenBank accession MT346027). 71  mRuby or LacZ coding sequences were inserted in place of sfGFP on the same plasmid backbone (pY71-mRuby, pY71-LacZ) for production of red fluorescence or LacZ enzyme, respectively. 52  The toehold switch sensor was Switch H selected from a publication by Pardee et al  48  and consisted of two plasmids pUCGA-swH-lacZ (switch) and pUCGA-trH (trigger) constructed as described by Blum et al. 52  Plasmid DNA was purified from transformed E. coli using commercial midiprep or gigaprep kits from a variety of vendors. Linear DNA encoding T7 polymerase-driven expression of colicin E1 with a 6xHis tag was amplified by a two-step PCR from plasmid pKSJ331 (a gift from Alan Finkelstein & Karen Jakes, Addgene plasmid #103063).
An agarose overlay was necessary to fully immobilize the PCL pieces for time course imaging since they did not adhere to the coverslip. Microscopy was performed over a 36 h time course as described below using mRuby and DIC imaging channels. The quantification of mRuby fluorescence signal measured by microscopy was performed using Zen Blue software (Carl Zeiss Microscopy, LLC). Quantification and normalization are further described in the supplemental information.
Clinical Outcomes Patient baseline characteristics and clinical outcomes were compared. Patient prognosis was assessed using acute physiologic assessment and chronic health evaluation II (APACHE II)  [50]  and SOFA  [51]  scores. Moreover, DIC and SIC were diagnosed using the International Society of Thrombosis and Haemostasis scoring at inclusion  [42, 43]. Data were collected from central medical records, including biological datasets that were routinely performed in patients that are admitted to the ICU such as platelet count, CRP level, coagulation assessment, renal function, and liver enzymology. Clinical outcomes were assessed 30 days and 1 year after ICU admission.
Statistics The analyses were conducted using GraphPad Prism Version 9 (GraphPad Software, San Diego, CA, USA). Continuous variables were expressed as the mean ± standard deviation and categorical variables were expressed as number and percentage. The data were subjected to the Kolmogorov-Smirnov normality test and Bartlett's test for homogeneity of variance. Log transformations were performed when appropriate. The categorical variables were analyzed using the Chi-squared test or Fisher's exact test, and the continuous variables using unpaired Student's t-test as appropriate. A log-rank test was applied to compare the ICU length of stay and ventilation duration. All p-values were two-sided, and p < 0. 05 was considered statistically significant.
Acknowledgments: The authors would like to thank all the patients for their participation in this study, as well as  Fatima Laarbaui ,  Olivier Van Caenegem ,  Sophie Pierard ,  Luc Jaquet ,  Philippe Hantson , and  Christine Collienne  for their help to enroll patients and  Suzanne Renard ,  Caroline Berghe ,  Marie-France Dujardin ,  Leslie Gieslen ,  Brice Lambert , and all ICU nurses for their help at collecting samples.
Given a parameter N > 1, starN is an automata network (Σ, S, T ) defined as follows. • Σ = {a i | 1 ≤ i ≤ N} • S = {a 1 0 , a 1 1 } × {a 2 0 , a 2 1 } × • • • × {a N 0 , a N 1 } 1 https://doi. org/10. 5281/zenodo. 7460388                         Figure 3: The State Transition Graph of star03 • T = {(a i 0 , a i 1 , {a j 0 | 1 ≤ j ≤ N, i = j}) | 1 ≤ i ≤ N} ∪ {(a i 1 , a i 0 , {}) | 1 ≤ i ≤ N}. Each starN automata network contains N automata that have two states, 2N transitions, and only one attractor of size N + 1. star03 is given below. 3  shows the attractor of star03 in gray. Bound k. For all benchmarks, the attractors are known. In this experiment, we set a bound k for each automata network so that solvers can compute the largest attractors. Environment. We execute all experiments on the machine that equips 3GHz CPU and 16GB RAM.
2. "+S" denotes the basic constraint model with the symmetry breaking constraint discussed in In the biologically inspired benchmarks, all methods solved them within a few seconds. The main reason is that they contain small-sized attractors and thus k is also small. The difference between the proposed methods and the ASP-based method mainly comes from the implementation language: C++ and Scala. The proposed method is implemented on Scala which is running on a Java Virtual Machine (JVM) for the modeling part and thus there is a small disadvantage on this point. One exception is T-helper which contains a large number of attractors. On this problem, our approach takes advantage of the SAT solver BDD_MINISAT_ALL dedicated to the fast enumeration of solutions. On star benchmarks, the difference between each method is more obvious.
ACKNOWLEDGEMENTS This work was financially supported by the " PHC Sakura" program  ( 43009SC ,  JPJSBP120193213 ), implemented by the  French Ministry for Europe and Foreign Affairs , the  French Ministry of Higher Education, Research and Innovation  and the  Japan Society for Promotion of Science. This work was also supported by  JSPS KAKENHI  Grant Numbers  JP20K11748  and  JP20H05794.
| MRI evaluation Anonymized baseline and follow-up MRI scans were centrally reviewed by a dedicated radiologist with 8 years of experience (VA), who was blinded to patients' clinical history (including survival). Data regarding MRI patterns according to EANO-ESMO diagnostic criteria (linear, nodular or both), sites of LM (infratentorial, supratentorial, spinal or a combination of the previous), presence of hydrocephalus and parenchymal brain metastases were collected. Type of LM according to EANO-ESMO diagnostic criteria (Type I defined by positive CSF cytology, type II defined by typical clinical and MRI signs) was also recorded. 2 or patients with evaluable follow-up MRI imaging, radiological response assessment on the first re-evaluation MRI after start of treatment for BC-related LM was centrally evaluated using the 2019 revised RANO LM response criteria.
| Statistical analysis Clinicopathological characteristics were described using standard descriptive statistics. Associations between variables were evaluated using chi-square test, Fisher exact test and t-test. Overall survival (OS) was calculated from date of baseline MRI and was estimated using the Kaplan-Meier method. Patients alive without event were censored at last follow-up. For evaluation of prognostic factors, Hazard Ratio (HR) and 95% confidence interval (CI) were calculated using the Cox proportional hazard regression model. All p values were two-sided, with significance level set at P <. 05. The Kappa coefficient was used to assess the agreement for overall response assessed using the 2019 revised RANO LM response criteria between the two radiologists. Statistical analysis was performed using IBM SPSS, version 25.
| Clinical-radiological characteristics and prognostic factors: overall study cohort From a comprehensive database of 225 consecutive patients diagnosed with BC-related LM, a total of 142 patients with a baseline brain MRI were identified and included in the present study (flow diagram, Figure  1 ). Patient and tumor characteristics of the 142 included patients are summarized in Table  1. Among the 142 patients included, 78 (54. 9%) patients had a positive CSF cytology and were classified as type I LM according to EANO-ESMO classification; for 64 (45. 1%) patients, CSF cytology was negative or not performed and leptomeningeal involvement was therefore classified as type II. Treatment administered for BC-related LM was heterogeneous. The majority of the 142 patients included in the present study received at least one treatment modality, either local, systemic or both, whereas 16 patients (11.
13 In addition, in the selected cohort of patients with a follow-up MRI, the prognostic impact of treatment modalities was also evaluated, and we confirmed the prognostic impact of systemic chemotherapy  [17] [18] [19] [20]  and hormone therapy. 15, 21 e major limitation of the present study is represented by its retrospective nature. For this reason, only radiological data could be accurately collected and assessed, while neurological and CSF assessments were unfortunately not always available. Moreover, spinal MRI was not available for the majority of patients. In addition, it should be pointed out that a large number of patients with BC-related LM were not able to perform a re-evaluation MRI, thus limiting the applicability of our considerations to a relatively selected group of patients.
Responders were defined as having complete response (CR) or partial response (PR) by RECIST V. 1. 1; non-responders were defined as having progressive disease (PD). Continuous molecular variables were compared between responder versus non-responder groups using the non-parametric Mann-Whitney Wilcoxon test. The Cancer Hallmark gene set enrichment analysis (GSEA) was performed using the R package "fgsea"  (27, 28). The study was designed to test the superiority of abemaciclib, trastuzumab, and fulvestrant (Arm A) or abemaciclib and trastuzumab (Arm B) to SOC chemotherapy and trastuzumab (Arm C) in improving PFS in the intention-to-treat (ITT) population, using the log-rank test stratified by the randomization strata.
Results The study enrolled 237 patients (1:1:1), with 79 patients in each arm and the 227 patients who received at least 1 dose of study treatment and were included in the safety population. At the time of data cutoff (  31 March 2022), 157 deaths had occurred across treatment arms; 50 (63. 3%) in Arm A, 54 (68. 4%) in Arm B, and 53 (67. 1%) in Arm C. Median follow-up was 52. 9 months.
4%, febrile neutropenia). S1. The RNA-seq data was then used to determine intrinsic subtypes using the Parker PAM50 classifier and Genefu. The final consensus subtype was assigned based on the subtype having the most frequent prediction across the methods. A high concordance was observed between the predictions from the Parker PAM50 classifier and Genefu, with higher concordance for basal, HER2-enriched, and luminal B subtypes compared to luminal A and normal-like subtypes. The predicted intrinsic subtypes were analyzed to determine if there was an association between subtype and clinical efficacy. Out of 153 samples, 8% were of the normal-like subtype, 8% were basal, 24% were HER2-enriched, 34% were luminal A, and 26% were luminal B. Luminal subtypes were associated with longer PFS and OS compared to non-luminal.
Acknowledgements This work was funded by  Eli Lilly and Company. Fulvestrant was provided by  AstraZeneca. Eli Lilly  and Company contracted with  Syneos Health  for medical writing assistance from  Ndidi Uzor, PhD , and editorial assistance from  Dana Schamberger , MA. The authors and  Eli Lilly  and Company would like to thank all patients and their families for participating in this trial, as well as the study sites, study investigators and their staff, the Assessment Committee members, and the clinical trial team, without whom monarcHER would not have been possible. Downloaded from http://aacrjournals. org/clincancerres/article-pdf/doi/10. 1158/1078-0432. CCR-23-1209/3379182/ccr-23-1209. pdf by guest on 03 June 2024 19 Tolaney et al. , 2023.
HRs and 95% CIs were estimated by means of the Cox proportional hazards regression model stratified by randomization strata. The effects of prognostic variables (stratification factors, intrinsic, and extrinsic factors) on treatment response were established by means of an unstratified Cox proportional hazards regression model in a prespecified subgroup analysis. Efficacy analyses and a description of patient and disease characteristics were based on the ITT population. The safety analysis population included all enrolled patients receiving at least 1 dose of any study drug. SAS version 9. 4 was used for all statistical analyses. This trial is registered at ClinicalTrials. gov, NCT02675231. Tolaney et al. , 2023 provided in a secure data-sharing environment. For details on submitting a request, see instructions at https://vivli.
ACLY activation involved in EC proinflammatory activation induced by LPS To investigate the changes of ACLY in vascular ECs under septic conditons, HUVEC were stimulated with LPS. We observed a time-dependent increase in ACLY phosphorylation, while the total expression of ACLY remained unaltered within 4 h of LPS stimuli (Fig. 3A, B ). To examine the role of ACLY activation in EC inflammation, HUVEC were pretreated with BMS-303141 before  E-G HUVEC were transfected with siRNA specific for ACLY before 4 h LPS incubation and analyzed for the expression of adhesion molecules using Western blot and the production of MCP-1 using ELISA (n = 4). H Transcriptomic analysis of HUVEC stimulated with 1 µg/mL LPS ± BMS-303141 for 4 h (n = 2). Expression data were log transformed and scaled. I GO analysis of DEGs between the LPS and BMS + LPS groups.