dataesr/scientific-paragraphs-categorization huggingface dataset:
VII. ACKNOWLEDGEMENTS prior to his untimely death. We dedicate this paper to memory. This work was supported in part by Established Career Fellowship EP/M017982/1 from the Engineering and Physical Sciences Research Council (REG & AIP), the Schlumberger Fund (REG), the National Research Agency (ANR-20-CE30-0019) (CR) and by the French government, through the UCAJEDI Investments in the Future project of the National Research Agency (ANR-15-IDEX-01) (CR).
A comprehensive, predetermined search strategy will be applied to the MEDLINE and Embase electronic databases from inception to December 2020. All clinical studies presenting su cient data on free tissue transfer performed on short-term surgical missions (STSMs) in LMICs will be eligible for inclusion. The primary outcomes are rate of free ap failure, rate of emergency return to theatre for free ap salvage and successful salvage rate. The secondary outcomes include postoperative complications and any functional or patient reported outcome measures. Screening of studies, data extraction and assessments of study quality and bias will be conducted by two authors. Individual study quality will be assessed according to the Oxford Evidence-based Medicine Scales of Evidence 2, and risk of bias using either the 'Revised Cochrane risk of bias tool for randomized trials' (Rob2), or the 'Risk of bias in non-randomized.
Search strategy The search strategy (Table  1 ) will be applied to the MEDLINE and Ovid EMBASE databases from inception to 2 nd January 2021. All clinical studies reporting outcomes of any microsurgical procedure performed on a short-term reconstructive mission to any low-income or middle-income country (in accordance with the world bank classi cation(28)) will be eligible for inclusion. Studies that match the inclusion criteria performed in lowresource environments in a high-income country will also be included. Children and adults will be considered. All cases performed using either operating microscope or loupe magni cation will be included, as both are successfully reported in resource-limited settings  (15). The Population, Intervention, Comparison, Outcome (PICO) model was used to determine study selection criteria (Table  2 )(29).
Additional data In addition to the primary and secondary outcomes, duration of procedure and length of stay will also be recorded where available. In the context of a STSM to a LMIC, this is particularly important. The following will also be extracted: bibliographic data (Title, author, date), study characteristics (design, method of randomisation/allocation, blinding, number of participants, groups/subgroups), mission characteristics (country, length of mission, type of mission/subspecialty, organisation (type and size), type of hospital (e. g. public or private), frequency of missions), patient characteristics (age, sex, indication for surgery, comorbidities, smoking status), intervention characteristics (Operation(s) performed, duration of operation, length of stay, who performed the surgery (local or visiting surgeon), experience level of surgeon who performed anastomosis and raised ap, pre-operative workup), and rate and duration of follow up.
Data management and extraction Abstracts will be screened on the Rayyan systematic review software tool. Full papers will be downloaded as PDFs, and stored locally on Mendeley Desktop. All abstracts included will proceed to full text analysis unless it is immediately apparent following reading of the introduction that they are irrelevant. Data items will be collected in a standardised data collection proforma. For instances of incomplete data, we will contact the corresponding author. If 2 weeks elapse with no response, we will repeat this request once.
Data selection Screening will be conducted and recorded in accordance with the Preferred Reporting Items for Systematic Review and Meta-Analysis (PRISMA) guidelines  (27). Abstracts screened according to criteria set out in this protocol by two independent researchers (HdB and UC). In case of disagreements: researchers will meet to discuss disparities; if there are still disagreements, a third author (CH) will make the nal decision on inclusion. If abstracts are not available on assessment, the paper will be downloaded in full for analysis.
Strategy for data analysis and synthesis Statistical analysis of included studies will be undertaken in Revman 5. 4 (Cochrane Collaboration, Oxford, United Kingdom). Patient demographics will be presented using basic descriptive statistics. Complications, free ap failure, emergency return to theatre and successful free ap salvage will be calculated and displayed as rate (%). Data from the rst UK National ap registry will be used as a comparator(8). Statistical heterogeneity will be examined by calculating I 2 and Cochran's Q statistic, and interpreted according to Cochrane guidance on determining heterogeneity(26). If I 2 >50, a random-effects model (DerSimonian and Laird with a logit transformation applied) will be used to calculate relative risk with 95% con dence intervals(36). If I 2 ≤50, a xed-effects model will be used for relative risk calculations.
A p-value of <0. 05 will be considered statistically signi cant. The results of this metaanalysis will be presented in Forest plots. Funnel plots will be used to detect publication bias. If quantitative analysis is inappropriate a narrative synthesis will be performed. The analysis detailed above will be undertaken for the pooled data. If su cient data is available, subgroup analysis by region (e. g. head and neck, trunk etc. ) will be undertaken. Con dence in cumulative evidence body of evidence underpinning of the ndings will be assessed according to the 'Grading of Recommendations, Assessment, Development and Evaluations' (GRADE) approach  (37). Using this approach, the authors will express their 'certainty' that the body of evidence re ects reality (High, moderate, low, very low).
We predict considerable clinical heterogeneity between the studies included in this paper. STSMs are often based on relationships between speci c institutions, sometimes individual surgeons, and thus there is no 'one size ts all approach'. Another source of heterogeneity will come from the inclusion of all ap types. We will try to mitigate this through sub-group analysis if possible, but there may be insu cient data available. Nutritional status has been identi ed as a determinant of free ap outcome  (39). STSMs treat a diverse population of patients, many of whom will have poor nutritional status. This may be a confounding factor in reconstructive outcomes, but is unlikely to be well documented in a standardised manner across the literature. We will collect nutritional and other preoperative assessments where possible, but there may not be su cient data to adjust for these variables.
A 60-year-old man was admitted for ablation of ventricular tachycardia (VT) following anteroseptal myocardial infarction. Cardiac computed tomography (CT) images were processed with ADAS-VT software  (Galgo Medical, Barcelona, Spain). Two large zones of septal and anteroapical wall thinning were found, separated by a very small zone of thicker wall. High-density electroanatomical mapping was performed using CARTO 3 and the PentaRay catheter (Biosense Webster, Diamond Bar, CA). Local abnormal ventricular activity (LAVA) and late potentials were observed between thinned segments. Two badly tolerated VTs could be induced, VT1 (right bundle branch block, superior axis) and VT2 (left bundle branch block, inferior axis). A pace-mapping strategy was pursued. Pace mapping along the area of the 6-10 mm wall thinning zone, between the areas of <6 mm wall thinning, matched both VT morphologies, demonstrating that activation proceeded along the exit or entry parts of the isthmus according to slight changes in the pacing site.
Clinical data Clinical and oncological data of patients from both the exploratory and validation cohorts (total n ¼ 221), stored in the database of the French Reference Center for Paraneoplastic Neurological Syndromes and Autoimmune Encephalitis, were collected by AV. Physicians in charge of the KLHL11-Ab positive patients were contacted in order to obtain information regarding the last follow-up, relevant neuroimaging data, pathological samples andwhenever available-videos of the last neurological examination. Design and validation of a clinical score for predicting Kelch-like protein 11 antibodies' positivity Since there is no commercial test available at the moment, very few laboratories in the world are capable of identifying KLHL11-Abs. Therefore, a secondary aim of this study was to design a clinical score for detecting those cases that, despite being seronegative for other neuronal Abs, are most likely to harbour KLHL11-Abs, and hence need to be tested at reference centres for PNS.
Statistical analysis Categorical variables were expressed as frequencies and percentages and continuous variables as median and range. The sensitivity, specificity and accuracy of the newly designed clinical score were calculated using MedCalc, version 19. 5. 3 (MedCalc Software, Ostend, Belgium). A prevalence of 1. 4 per 100 000 persons for KLHL11-Ab syndrome (previously described in the Olmsted County, MN, USA)  1  was considered for the calculation of the diagnostic performance of the score.
Acknowledgements The authors thank  NeuroBioTec ,  Hospices Civils de Lyon BRC (France ,  AC-2013-1867 ,  NFS96-900 ) for banking sera and CSF samples. They also thank  Dr Elsa Poullot  for providing a pathological sample. We gratefully acknowledge  Dr Helene Boyer  for  English language editing (Direction de la Recherche Clinique et de l'Innovation ,  Hospices Civils de Lyon ).
MATERIALS AND METHODS EF-14 (NCT00916409) was a multicenter, phase 3, open-label, randomized clinical trial that assessed the efficacy and safety of TTFields (200 kHz) plus maintenance TMZ combination versus maintenance TMZ monotherapy in 695 patients with ndGBM  (13). All patients provided written informed consent prior to entering the study. Patients with newly diagnosed, histologically confirmed supratentorial GBM, with a KPS score of ≥70, and who were progression-free following debulking surgery or biopsy and standard radiotherapy with concomitant TMZ were eligible to enroll. Subjects were randomized 2:1 to receive TTFields plus TMZ chemotherapy or TMZ monotherapy. TMZ was administered to both groups (150-200 mg/m 2 ) for 5 days per 28-day cycle (6-12 cycles)  (13). TTFields (200 kHz) was delivered from a portable device (Optune ® , Novocure ® GmbH, device manufacturer) via 4 panel arrays with 9 ceramic disks of each panel placed on the shaved scalp for a recommended monthly average usage of ≥18 h/day.
Ethics The study was approved by the local independent ethics committee (Comité de Protection des Personnes Est II, Besançon, France; reference: 17/07, June 19, 2017) and was registered at Clinicaltrials. gov (NCT03478709). The present report was drafted in line with the STARD statement  (Bossuyt et al. , 2015). The study complied with the tenets of the Declaration of Helsinki. All patients provided their written informed consent to participation.
MSP and CCP The MSP and CCP were measured using the inspiratory breathhold maneuver described by  Maas et al. (2012). The measured venous and arterial pressures were plotted against cardiac output (CO), and a linear regression line was fitted to the data points. The MSP was determined by extrapolation of the central venous pressure (CVP) to zero flow on the venous return curve. The CCP was determined by extrapolation of the arterial pressure to zero flow on the ventricular output curve. Indexed SARi (mmHg ml -1 •m -2 ) was calculated as (MAP -CCP)/CI. Indexed systemic venous resistance (VRi, mmHg ml -1 •m -2 ) was calculated as (MSP -CVP)/CI.
Statistical Methods We calculated that a sample size of 14 patients would allow to demonstrate a correlation between Ea dyn and CCP higher than 0. 5, using Spearman's correlation coefficient with a risk alpha of 5% and a power of 80%. The distribution of the variables was assessed using the D' Agostino-Pearson test. Data are expressed as proportion (%), mean (standard deviation), or median [IQR] (interquartile range) as appropriate. Paired data were compared using Wilcoxon signed rank test. Linear correlations were tested using Spearman's rank method. Associations between arterial load and blood flow parameters measurement considering both time points were assessed using mixed linear modeling. Only bivariate models were carried out. Ea dyn was the dependent variable; each hemodynamic variable was used as fixed effect, and individual was used as random intercept.
The normality of the distribution of random effects and of the model residual were graphically checked. Because this analysis was exploratory, slight disparities between those distributions and normality were tolerated. The threshold for statistical significance was set to 0. 05. Statistical analysis was performed using RStudio Version 1. 1. 447-2009-2018 RStudio, Inc. , and SPSS ® software (version 24, IBM, New York, NY, United States).
Study design Data were obtained from the older cohort of the Young Lives (YL) study, an international and longitudinal cohort survey performed in Ethiopia, India, Peru, and Vietnam. 20  The YL study employed a clustered multistage sampling strategy in each country. At the first stage, 20 sentinel sites were selected in each country by semi-purposive sampling with slight oversampling of poor sites to serve the main study objective to explore the causes and consequences of childhood poverty. 20 For example, the most food-insecure areas encompassed the sampling universe in Ethiopia. In Peru, the richest 5% of districts were excluded from the sample. However, final samples represent a range of regions, policy contexts, and living conditions. 7 The cohort in India consisted only of households from Andhra Pradesh while cohorts in the other three countries were nationwide.
In a developing country context, sharing seeds and livestock breeds can be one of the examples. Further, in communities with strong ties, solidarity, and networks, people can share the food itself during times of hunger. 19 However, our analyses revealed that the child's nutritional status was associated only with financial support both for mother and child, and food security was not a mediator. There are several possible explanations for the lack of mediation by food insecurity. First, the YL study over-sampled poor sites, and the data from India were collected only in the state of Andhra Pradesh which is one of the poorest states. Therefore, food would not have been sufficient across the community. Even if someone had social supports these sources of supports might have not had enough food to share.
Future research needs to repeat the current analysis using more sophisticated measurements of social support (i. e. , measuring strength and frequency of support) and based on a more recent dataset with a larger sample size to confirm the findings. Ethical Approval and consent to participate. Young Lives Study provides anonymous, secondary data that is publicly available for scientific use. We downloaded the data without identifiers; thus, the confidentiality of the information given by the participants was guaranteed. Therefore, ethical approval was not required. Participants provided signed informed consent before the study commenced and were assured of confidentiality.
2012 , Siddique et al. 2015). This opens questions regarding the phylogenetic extent of transparency, the diversity and evolution of optical properties and of the underlying structures, the existence, if any, of structural constraints on transparency, and the ecological relevance of transparency on land. Using a large data set comprising 123 clearwing Lepidoptera species encompassing 31 families, we examine the phylogenetic distribution of transparency in Lepidoptera. Theoretical and empirical studies on aquatic organisms suggest there exist several structural and optical routes to transparency  (Johnsen 2001) , highlighting the interest of quantifying structural diversity in terrestrial organisms. First, we aim to quantify the extent of structural diversity for transparency in Lepidoptera at various scales: macrostructure (wing size, wing area, clearwing area, and proportion of clearwing area) and microstructure (presence of scales, type, insertion, and coloration).
We analyzed spectral shape using Avicol v6 (available online) 9  and the pavo R package  (Maia et al. 2019)  to A structural strategy is defined as the combination of scale type, insertion, and coloration. Type is P, piliform scales, or L, lamellar scales (the combination of piliform and lamellar scales was assimilated to lamellar scales); insertion is E, erect, or F, flat; and coloration is C, colored, or T, transparent. The N strategy has no scales, no insertion, and no coloration. Bar scales are 1 cm for entire specimens (left columns), 100 μm for microscopic imaging (right columns and scale details). Species are the erebid Senecauxia coraliae (SE), the psychid Chalioides ferevitrea (CH), the nymphalid Pseudohaetera hypaesia (PS), the saturniid Attacus atlas (AT), the erebid Isostola flavicollaris (IS), the hesperid Oxynetra semihyalina (OX), the papilionid Cressida cressida (CR), and the crambid Diaphania unionalis (DI).
These species were chosen of the same subfamily or, if not possible, in the same family to get three to five species per family. We thus obtained a set of 183 species to build the tree. We used DNA sequences for the mitochondrial COI and COII genes, and for the nuclear CAD, EF1, GADPH, IDH, MDH, RpS5, and wg genes (Supplementary file File2_SpeciesSequences. txt). We aligned the sequences with CodonCodeAligner (version 4. 2. 7, CodonCode Corporation, available online) 10  and concatenated them with PhyUtility (version 2. 2,  Smith and Dunn 2008). The data set was then partitioned by gene and codon positions and the best models of substitution were selected over all models implemented in BEAST 1. 8. 3  (Drummond and Rambaut 2007) , using the "greedy" algorithm and linked rates implemented in Partition Finder 2.
Statistical analyses All analyses were conducted using the R environment (R Development Core Team 2013). Data used for the analyses are available as supplementary files (File3_Da-ta_AllColors. txt and File4_Data_SpeciesMeans. txt). Repeatability analysis. -We assessed the repeatability of optical and structural parameters, using the rptR package  (Stoffel et al. 2017). For transparency measurements, we took the five measurements as repetitions of the same species and wing. For wing length, we measured each wing twice and thus obtained two repetitions of the same wing for each species. Regarding the repeatability of the measurements of scale density, length, and width, we measured a small number of scales of the same type, zone, and wing, and tested whether within-group variability was lower than between-group variability.
All measurements were found highly repeatable (see sample sizes and results in Appendix S1: Table  S2 ). Phylogenetic signal and phylogenetic clustering. -We implemented two complementary approaches to estimate the statistical nonindependence among structural trait values due to species phylogenetic relatedness. First, we estimated the amount of phylogenetic signal in each structural and optical variable. For continuous variables, we used both Pagel's lambda  (Pagel 1999 ) and Blomberg's K  (Blomberg et al. 2003)  implemented in the phytools R package  (Revell 2012). For binary variables, we used Fritz and Purvis' D  (Fritz and Purvis 2010)  implemented in the caper R package  (Orme et al. 2018). Second, we assessed to what extent structural features and structural strategies were phylogenetically conserved, in other words we estimated the degree of phylogenetic clustering for structures.
We calculated the mean pairwise phylogenetic distances (MPD) for each categorical structural parameter  (Webb 2000) , using the picante R package  (Kembel et al. 2010). MPD measures the average phylogenetic distance that separates two species sharing a specific trait state. We computed MPD values for the forewing and the hindwing separately, or for both the forewing and the hindwing (in that case we considered all the species that presented the trait on at least one of the wings, the forewing or the hindwing). For a specific trait, we first computed the observed MPD, and then simulated MPD distribution by randomly shuffling trait values on the phylogeny. We then determined whether the observed value was lower than the 5% lower quantile of the distribution of simulated MPD values, in which case we concluded that the trait was found in species separated by fewer nodes than expected by chance.
Correlated evolution between structural traits. -To assess whether scale presence, type, insertion, and color evolved in a correlated fashion both within and across transparent and opaque zones, we computed Pagel's discrete model for those binary traits and compared the likelihood values from the dependent and independent models, using the FitPagel function, assuming a general formulation of dependency (ARD, i. e. , all transition rates being different and the transition rate on character 1 depending on the state of character 2 and vice versa) from phytools  (Revell 2012). General statistical approach for structural constraints, structure-optics relationships, and ecological relevance. -We conducted (1) mixed models using the nlme R package  (Pinheiro et al. 2020 ) and (2) Bayesian phylogenetic mixed models with Markov Chain Monte Carlo analyses using the mulTree R package  (Guillerme and Healy 2019).
ACKNOWLEDGMENTS This work was funded by Clearwing  ANR  project ( ANR-16-CE02-0012 ),  HFSP  project on transparency ( RGP0014/2016 ) and a  France-Berkeley fund grant  ( FBF #2015---58 ). We thank  Peruvian and Ecuadorian  authorities to allow us conducting fieldwork that inspired this study (authorizations 373-2017-SERFOR-DGGSPFFS,  019-IC-FAU-DNBAPVS/MA ). We warmly thank  Jacques Pierre  and  Rodolphe Rougerie  for help with species choice, identification, and data on species ecology,  Edgar Attivissimo  for contributing to Keyence imaging, and  Thibaud Deca€ ens ,  Daniel Herbin , and  Claude Tautel  for species selection and identification. We thank  Axel Hasmann ,  Ulf Buchsbaum , and  Gottfried Behounek ,  Jayme Sones ,  Jeremy deWaard , and  Franz P€  uhringer for giving us access to private.
The sample was essentially composed of workers from health (24%) and social (22%) sectors. Workers from administration (20%), high distribution (18%), and educational (16%) sectors also participated. The sample was 85% female with an average age of  35. 10 (SD = 11. 19 ). Most of the workers were from the public sector (47%), had a tenure to their organizations longer than 1 year (79. 4 %) and worked in team context (89. 4%). The majority of participants were employees without managerial responsibilities in their organization (63%) and had a degree at least equivalent to bachelor (71. 8%). We collected data at three points in time to analyze the effect across time of our hypothesized model and to reduce the potential for common method variance  (Podsakoff et al. , 2003). We aimed at a starting sample of 1,000 participants to Time 1 to ensure an adequate sample at Time 3.
In the last two decades, various Monte Carlo-based internal dosimetry programs or routines have been applied  [24] [25] [26] [27] [28] [29]. Despite being considered the gold standard, they all differ in complexity and have not been integrated in the clinical practice yet, except in few centers for research purposes only. The main reason is that they usually require very high computer performances and calculation time, which are not compatible with the daily clinical routine. A second reason is often the lack of validation processes. This work deals with the physical validation of a novel treatment planning system (TPS) named MCID (MC Internal Dosimetry tool)  [30, 31] , performing Monte Carlo-based voxel dosimetry, applied to 90 Y-radioembolization of liver malignancies. Patient's CT and SPECT can be imported in MCID software, which creates different macros, i.