dataesr/scientific-paragraphs-categorization huggingface dataset:
Control totals for tax units and individuals The sources for the three steps identified in the text are set out in Table  2 , covering (1) total population (described in Sect. 3), (2) the age structure of the population and (3) marital status for women. Data on the population by age has been interpolated from yearly figures obtained from publication P0302 (Table  6 ) for 2006, the censuses for 2001 (Table  4. 3) and 1996 (Table  2. 16), and data from the United Nations (1994), which give the age composition at 5-year intervals from 1990 back to 1950. For the period prior to 1990, the number of tax units is obtained from the number of people aged 15 and over minus the estimated proportion who are married women. The ratio of married women to those aged 15 and over is taken from the census of population for those years where all races are covered  : 1911, 1921, 1936, 1946, 1951, 1960, 1970, 1980 and 1991.
The first exploratory controlled trial suggests that computer-assisted instruction treatment is efficient  (25). The second preliminary exploratory study showed promising results with a robot-assisted handwriting activity. Authors used an iterative design and evaluation protocol to define a robot-assisted handwriting activity related to the shape and the dynamics of the letters. Their scenario combined specific computerized instructions and pupil-robot interaction through haptic properties of the robotic platform Cellulo to offer interactive feedbacks  (26). Here, we present (1) the Co-writer setup that combines several modules (a Wacom tablet, a Naorobot, a 2D camera to assess posture, specific metrics to assess writing, and a platform of serious games-Dynamico) in the context of a learning-by-teaching scenario (27); (2) how we used this setup to reopen handwriting therapy in a child with complex NDD associated with dysgraphia and refusal to write.
Features have been detailed in Asselborn et al. (23). The second component is a robotic platform Nao that remains beside the child. We previously showed that participants' engagement was better with a physical robot than an avatar  (29). During sessions, the child writes with a stylus on a Wacom Cintiq Pro connected to a laptop. Ubuntu was installed on the laptop with the Cowriter software  (30). We asked the child to teach Nao how to write. One after another, Nao pretends to write on the Wacom tablet by moving its arm, and the child writes on the tablet to correct the writing of the robot. The cowriter research project aims to help children with difficulties using an original approach: the child plays the role of the teacher and the robot acts as a student requiring help to improve its handwriting.
Notably, for each extracted point, the OpenPose library exposes a confidence measure (p). The temporal evolution of the key points is then reconstructed using the frame rate of the camera. To ensure a reliable comparison between the metrics extracted from different videos captured on different days, the camera was fixed in its specific position, thanks to markers on the floor. Moreover, to minimize further possible errors, data were normalized among videos using the distance between the child's left eye and his left ear as a fixed, reliable reference, simple to compute. A metric indicating the quality of the child's posture was defined as the distance between his nose and his right hand since R was right-handed. This metric can be interpreted as a reflection of the body posture in the median anatomical plane.
FUNDING This project was funded by the  Assistance Publique Hopitaux de Paris  (APHP, concours de la médaille),  Paris 8 University , the  Agence Nationale pour la Recherche  (Grant number:  ANR-19-CE19-0029 ), the  Fond National Suisse pour la recherche scientifique  ( FNS, grant name Irecheck ), and the  Center pour les Activités de Recherche en Psychiatrie Infanto nile Juvénile (CARPIJ).
The existence, precise location and knapping suitability reported for the Iranian obsidian outcrops also remain uncertain, although recent fieldwork has started to tackle this specific issue in more detail  (Niknami et al. 2010; Abedi et al. 2018a; Orange et al. 2020). Despite these limitations, over 5000 artefacts have been analysed in the last 50 years. For a list of the data published in close to 30 selected publications, see Supplementary Data 1 in the additional supporting information. While this represents a large number of artefacts, it should be noted that these data were obtained from no fewer than 96 sites, encompassing a long time span (Palaeolithic to Iron Age), in a region where obsidian is omnipresent and has been used abundantly. The proportion of the assemblages that have been analysed is rarely representative of the whole industry-a parameter that can only be assessed when the total number of artefacts is indicated.
Addressing the heterogeneous data on the obsidian sources of the area As a first step, the incredible wealth of available data on the obsidian sources of the Caucasus and eastern Anatolia had to be sorted out. While a considerable amount of information is summarized in both the literature (e. g. ,  Blackman et al. 1998; Poidevin 1998; Badalyan et al. 2004; Chataigner and Gratuze 2014a ) and online (Obsidatabase; Varoutsikos and Chataigner 2010), a certain amount of confusion is still perceptible when archaeologists refer to obsidian sources. This confusion is mainly due to the variety of names used for each source by different authors (e. g. , the names 'Choraphor', 'Khoraphor', 'Khorapor', 'Vardenis', 'Karnyjarykh' and 'Karnyajarich' all designate the same source). Following the work of  Mouralis et al.
(2018) , we have set up a standardized nomenclature for the numerous outcrops located in the Caucasus and eastern Anatolia, in collaboration with the GeObs team (https://geobs. univ-rouen. fr/). This nomenclature is presented in Supplementary Data 2 in the additional supporting information with an updated synthesis of the available information on the sources. We hope that this new frame will serve as a reference for future studies and promote comparisons between obsidian sourcing programmes region-wide, and also help clarify the resulting data for specialists working outside this specific field. The PAST-OBS and SCOPE projects also included the creation of an exhaustive geological database in order to identify the provenance of the obsidian used in Late Prehistoric assemblages. To that effect, we selected over 250 geological samples from the IRAMAT-CRP2A and IRAMAT-CEB collections, which serve as a reference for identifying the provenance of obsidian artefacts.
ACKNOWLEDGEMENTS The MBA (2006-ongoing, Director  C. Marro ) is funded by the  French Ministry of Foreign Affairs (MAEE)  and the  CNRS. Archaeological operations in Nakhchivan are conducted by  V. Bakhshaliyev  and  C. Marro. The  PAST-OBS  project (Director F. -X. Le Bourdonnec) was supported by the  ANR  ( LaScArBx LabEx ,  ANR-10-LABX-52 ). The  SCOPE  project is funded by the  University of New England  ( UNE PDF scheme ). The surveys led by  A. Abedi  in Iran are part of a project conducted at the  Tabriz Islamic Art University  (no. 7938/1  and  1398/05/ 01  and code no. 181 ); the authors thank this institute for providing the facilities and funding for this research. This work could not have been possible without the support of  M. Moore ,  L. Weeks  and  P. Grave  ( UNE ), and  R.
Unfortunately, data related to other diversity axes (i. e. , people belonging to underrepresented groups such as racial/ethnical minorities, LGBT+, disabilities or other gender identities) were not available. Therefore, it was not possible to analyze the participation of other genders and the intersection between gender and their belonging to other underrepresented groups and identities. Yet, it is worth noting that all attendees that responded to the post-conference anonymous online survey self-identified as either man or woman, despite the option "other gender" was also available. We examined potential gender imbalances in attendance and presenters by comparing women and men's representation for all data pooled together, as well as for each contribution type and career stage separately. We also analyzed potential gender imbalances in authorships by analyzing the proportion of women and men signing as first and last author of all contributions.
Audience and questioners during Q&A sessions A team of 26 volunteers took notes on gender distribution and the questioning behavior of the audience during the scientific sessions (Fig  1 ). Volunteers did not participate in the session nor explain the study to third parts. This procedure allowed us to observe the behavior of the attendees without conditioning it. To ensure that data from all observers was comparable, we generated a standardized template with all questions and trained all volunteers prior the observations (S1 Appendix). For each talk, volunteers wrote down the number of attendees and questioners by gender as well as the gender of the conveners and speaker (S1 Appendix). We acknowledge that the gender recorded by the observers might not match with the gender identity of the person in some cases.
In total, we collected data from 218 talks (56% of the total), including seven plenaries, 12 keynote, and 199 regular talks. Poster contributions were not analyzed. To account for differences among observers, 50% of the talks were evaluated by more than one person (2-6 observers). For questions related to the number of attendees and questioners, we averaged the values obtained from all observes (inter-observers' variability was < 5%). For gender-related questions (i. e. , those whose answer was "man" or "woman"), the most frequent answer was computed. Yet, discrepancies in gender-related questions only occurred on five occasions (2. 3% of the talks). For each talk type, we used t-tests to analyze (i) if the gender distribution of the audience was similar to that of the conference registration and (ii) whether the number of attendees differed between female and male speakers.
Hence, we consider that it did not affect the results. For each question, we fitted GLMs using Gaussian error distributions for Likert scale questions and Binomial error distributions for binary response variables. Each model included gender and career stage as predictors. Final models did not consider the interaction between gender and career stage because it was not significant in any initial model. Then, we used chisquared tests to determine whether respondents' gender or career stage influenced their answers. We ran all statistical tests in R 3. 6. 1  [36]. For all analyses, differences were considered significant when p-value < 0. 05. In all cases, model residuals were visually inspected to verify linear model assumptions of normality and homoscedasticity. The code and data used in this study can be accessed in https://github.
Acknowledgments We thank the support of the  Iberian Society of Ecology (SIBECOL) , in particular the president,  Cèlia Marrase , and the conference organizing committee. We are very grateful to the team of volunteers that helped collecting observation data during the conference (alphabetically):  Mireia Banque ,  Laura Blanquer ,  Mı ´riam Colls ,  Veronica Granados Perez ,  Margarita Menendez ,  Laura Roquer ,  Jordi Rene-Mor ,  Clara Ruiz-Gonzalez , and  Cristina Romera-Castillo. We also thank  Dolly Kothawala  and  Anne M. Kellerman  for English revisions. One anonymous reviewer and  Sandra Hille  helped to improve an early version of this manuscript.
FCT/ MCTES  ( UIDP/50017/2020 + UIDB/50017/ 2020 ). CG-C was supported by the  Spanish Government  through a  Juan de la Cierva -Incoporacio  ´n contract ( IJC2018-036642-I ). FL had a doctoral grant funded by  FCT  ( PD/BD/52598/ 2014 ). GO was supported by the  German Federal Ministry of Education and Research  within the  Collaborative Project "Bridging in Biodiversity Science -BIBS " ( 01LC1501A-H ). SP was supported by a postdoctoral fellowship  MSCA Seal of Excellence of the Research Foundation -Flanders  ( 12ZZS21N ). The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
The Japanese sample consisted of 2,612 individuals and the French sample of 3,791 individuals. To identify statistically significant differences between the two samples, Fisher's exact test and bootstrap approaches was used (boot package in R software). Sports participation and voraciousness for sport are higher in the French population than in the Japanese one. For the overall rate of sports practice, there is a difference of 8. 2 points (95%CI [6. 0;10. 3], p<0. 001), and the difference concerning the average number of activities practised by practitioners is 1. 7 activity (95%CI[1. 9;1. 5], p<0. 001). In both countries, young males have the highest level of sportiness. Age is an important variable with a lower difference between the youngest and oldest age groups for sports participation in Japan than in France: when compared to France, the difference in difference for the rate of no activity is 13.
The selection of two comparable surveys In quantitative sociology and for an international comparison with a societal approach, the primary collection data is very expensive and is very complex. That's why our analysis of data was a secondary analysis: the surveys have originally been designed by different researchers and for different purposes  [35]. Difficulties in understanding Japanese surveys and differences in language and culture  [36]  created problems in finding data concerning the relationship between the Japanese population and PSAs, as well as in translating and interpreting the questionnaire and the questionnaire database. Two English-language sources guided the research: a Nippon foundation's sports-life survey  [37]  and Wolfram Manzenreiter's book Sport and Body Politics in Japan  [38].
An initial comparison was then made using two national surveys, one Japanese and one French, carried out in the summer of 2016 (Sport life survey 2016, Baromètre National Sports de nature 2016). They served as a source for the investigation. Both are the result of a series of national surveys conducted over a period of at least 25 years. In the Japanese survey  [39] , data was collected from people aged between 18 and over, living in Japan and taking part in sports and physical activities. All data were fully anonymized before we accessed them. Questions focused on the frequency, duration, intensity and range of the activities, including spectating and sports volunteering. The data was gathered via an official home visit survey, either by handing over the paper questionnaire and retrieving it a week later or face-to-face if the questionnaire was not self-administered.
In total, data was collected on 3,000 individuals. There were 300 locations (273 cities and 27 towns/villages) and the extracting method was by quota (based on gender, age and region). The survey period was June 10th to July 10th, 2016. The survey crude sample characteristics are in Table  1. In the French survey  [40] , data was collected via an online, self-administered questionnaire from people living in France and aged between 15 and 70. All data were fully anonymized before we accessed them. Questions focused on sport and physical activity participation (and especially outdoor sports), motivations and sport-related expenditures. In total, data was collected on 4,014 individuals selected by quota. A final reweighting was performed based on gender per age, household size, diploma, region and town size.
We carried out a secondary analysis, that is to say that we have yet our two samples and do not try to define a future sampling scheme. The aim is simply to check if the given samples sizes are able to detect differences to avoid a type II error. We performed a statistical power analysis based on power calculations according to Cohen  [43]  using the pwr and PASSED packages  [44, 45]  on R software for comparing means with binary or count data. In line with Cohen's rules of thumb, we used the conventional threshold of 0. 8 for the power of test and an alpha level of 0. 05 (two-sided). The aim was to compare percentages of binary data (for instance the rate of no activity) and means of count data (the number of PSAs) between the Japanese sample and the French sample. The distribution of the outcome variable for binary data is Bernoulli (pwr.
Univariate and bivariate analyses were computed using R 3. 5. 2 statistical software  [46]. Concerning univariate analyses, 95% confidence intervals were performed with bias-corrected and accelerated ("bca") confidence intervals which are a refined version of the percentile bootstrap (resampling method to mimic the sampling process), using the confintr R package  [47]  with ci_proportion and ci_mean R functions. For each confidence interval, 50,000 resamples were drawn from the survey dataset with replacement  [48]. Bivariate analyses were conducted using bca confidence intervals (50,000 resamples) with ci_mean_diff R function (confintr R package). Concerning the bivariate statistical tests, we computed p-values using Fisher's exact test to test the differences in proportions (analysis of a 2 × 2 contingency table with the fisher.
ACKNOWLEDGEMENTS The  EU-PEARL  Project has received funding from the  Innovative Medicines Initiative 2 Joint Undertaking (JU)  under grant agreement No  853966. The JU receives support from the  European Union 's  Horizon 2020 research and innovation programme and EFPIA and CHILDREN'S TUMOR FOUNDATION, GLOBAL ALLIANCE FOR TB DRUG DEVELOPMENT NON-PROFIT ORGANISATION, SPRINGWORKS THERAPEUTICS INC.
Statistical Analysis The Mean, Standard Deviation, Skewness, and Kurtosis of each item of the Transcultural Community Resilience Scale were computed and examined. Exploratory Factor Analysis (EFA) and Confirmatory Factor Analysis (CFA) methods were used to estimate the underlying components of Community Resilience among the population. The combined sample was randomly split in half considering each country; sample 1 (n = 615) was used for EFA and sample 2 (n = 652) for CFA. Prior to the extraction of the factors, the Kaiser-Meyer-Olkin (KMO) test and Bartlett's Test of Sphericity were conducted to assess the suitability of the data to factor analysis. A KMO value >0. 8 and significant specificity test indicate good sampling adequacy  (Bartlett, 1950; Kaiser, 1970; Tabachnick and Fidell, 2007).
Values of RMSEA <0. 06, CFI and AGFI >0. 9 indicate a good fit of the data  (Bollen, 1989; Hu and Bentler, 1999). In view of the increasing critical comments regarding Cronbach's alpha as internal consistency measure, we have also decided to calculate the coefficient H and the McDonald's Omega  (McNeish, 2018). Pearson bivariate correlation analyses were also performed to study the concurrent validity of the T-CRS using scores of depression and individual resilience. Analyses were conducted using SPSS Version 27 and Statistica Version 12.
μCT images of BY1 "High-resolution μCT images of the lower deciduous canine BY1 were obtained with the following scan parameters: 125 kilovoltage (kVp), 120 μA, and 0. 015 mm voxel size. The μCT volume was segmented using Avizo 9. 2 software (Thermo Fisher Scientific, Waltham, Massachusetts, US), and the 3D models of the dental tissues (i. e. , enamel, dentine and the preserved portion of the pulp chamber) were refined in Geomagic Design X (3D Systems Software, Rock Hill, South Carolina, US) to optimize the triangles and create fully closed surfaces. The morphological description of BY1 was performed according to standards outlined by the (ASUDAS  [34] ) Although ASUDAS has been devised for modern human permanent dentition, we applied protocol to fossil deciduous tooth as already done in other publications [e.
g. ,  [35] [36] [37]  because it permits a more precise and accurate comparison at each degree of development. The wear stage of the occlusal surface was assessed based on  [38] , while the age of root resorption was estimated according to Moorrees et al  [39, 40]. The crown diameters of BY1 were virtually measured in Geomagic Design X, orienting the tooth with the best-fit plane computed at the cervical line parallel to the xy-plane of the Cartesian coordinate system, and with the lingual aspect parallel to the x-axis. The size of the bounding box enclosing the crown was used to collect mesiodistal (MD) and buccolingual (BL) diameters. Comparative data for the BL diameter was collected from the literature  [40] [41] [42]. The computation of the 3D average enamel thickness (AET) and relative enamel thickness (RET) index follow  [41].
A set of Neanderthals (NEA; n = 6), early H. sapiens (EHS; n = 2), and recent H. sapiens (RHS; n = 3) lower deciduous canines at different wear stages was acquired using a Skyscan scanner with voxel size ranging from 13 μm to 74 μm) at the Department of Human Evolution of the Max Planck Institute for Evolutionary Anthropology. As for BY1, dental tissues were segmented in Avizo 9. 2 software, and the digital models were refined in Geomagic Design X. The 3D AET index (in mm) is the enamel volume divided by the underlying EDJ surface, while the 3D RET index (scale-free) is the 3D AET divided by the cube root of the crown dentine and pulp volumes.
Radiocarbon dating Thirteen charcoal samples collected from GH 5, 4, 3, and 2 were submitted for 14 C dating to the Klaus-Tsichira-AMS facility of the Curt-Engelhorn Centre in Mannheim, Germany. Prior to dating, the samples were pretreated with the ABOX method and dated  [43]  in the radiocarbon lab. For samples that yielded finite conventional ages, calendar-year ages (and the corresponding 68. 2% and 95. 4% confidence intervals) were estimated using the IntCal20 calibration dataset  [44].
Eight of the twelve samples were successfully dated, while one returned a minimum date (Tables  5  and 6 ). All the 14 C results are calibrated using the new IntCal20  [43]  within the OxCal 4. 4 program  [43, 49]  and are discussed here at 68. 2% probability. The youngest occupation of the site, corresponding to the Epipalaeolithic level, ranging between 13,400 and 13,300 cal. BP (Fig 9 ) Only two of the six charcoal samples from the UP GH2 were dated successfully (both from square G27: MAMS-41723 and MAMS-41725). The two ages obtained are consistent with each other, yielding calibrated age ranges of 34,700-34,400 and 34,600-34,400 cal. BP, respectively (Fig 3B  and Table 5 ). Five of the six charcoal samples collected from MP occupation layers (GH4 and GH5) produced reliable radiocarbon ages; a fifth sample produced a minimum age.
The MP-UP transition in Europe which started between 47 kya BP overlapped with the spread of Homo sapiens and Neanderthals around 40 kya. Recent Palaeogenetic studies show that the gene flow between Neanderthals and Homo sapiens have occurred in roughly between 60-50 probably in southwestern Asia  [62, 63]. This new information is consistent with the data from Bawa Yawan. The Bawa Yawan Neanderthal suggests an extirpation date of around 45,000-40,000 cal. BP, but the lithic evidence shows extend for a while. If the conditions under which Neanderthals became extinct, locally and overall, are to be determined, it is necessary to develop a more integrated approach to the problem.
Acknowledgments We are grateful to  T. Higham ,  K. Douka , who kindly provided radiocarbon dating (sample number  OxA-36752 ) for this project, and for useful discussion on the paper. We thank to a number of people who assisted us on this project late  M. Azarnoosh ,  Y. Moradi ,  H. Chubak ,  A. Tahmasebi ,  F. Biglari ,  R. Shirazi  ( Iranian Center for Archaeological Research ),  B. Omrani  ( Research Institute of Cultural Heritage and Tourism ),  A. Gillies ,  K. Janin ,  N. Hyedari ,  A. Tahmasebi ,  S. Kermajani ,  G. Weniger ,  R. Azizi ,  N. Naderian ,  E. Fotuhi , more specifically the excavation crew, the  Heydari  family and the local residents of Yawan village.