dataesr/scientific-paragraphs-categorization huggingface dataset:
8 years, 61. 1% men). Five distinct body silhouettes trajectories over the lifespan were identified: 31. 9% 'lean stable', 11. 1% 'lean increase', 16. 1% 'lean-marked increase', 32. 5% 'moderate stable' and 8. 4% 'heavy stable'. Subjects with a 'heavy-stable' trajectory (OR 1. 24, 95% CI 0. 94 to 1. 62) and those with a 'lean-marked increase' trajectory (OR 1. 46, 95% CI 1. 18 to 1. 81) were more likely to have EDS when compared with the 'lean-stable' group after adjusting for confounding. Further adjustment for birth weight strengthened the magnitude of the ORs. Conclusion Increasing body silhouette and to a lesser extent constantly high body silhouette trajectory from childhood to adulthood are associated with increased likelihood of EDS, independently of major confounding variables. trial registration number NCT00741728; Pre-results.
statistical analyses To construct body silhouette trajectories, we selected subjects who reported their body silhouettes for at least three age periods among the five, including necessarily the earliest and the latest period. Since body silhouettes across the lifespan are longitudinal data, we used a groupbased trajectory modelling implemented by SAS Proc Traj. 30 We identified five body silhouette trajectories, Open Access based on the change in the Bayesian information criterion (figure  2 ). Then, we calculated the posterior probability for each participant to belong to each of the five trajectories and attributed the participant to a trajectory according to the highest probability. The average probabilities for each group were 86%, 89%, 79%, 89% and 91%, indicating a good allocation of subjects among trajectories.
Analysis was initially performed by sex, but trajectories were almost identical between men and women, and there was no significant interaction between sex and group-based trajectories (p value for interac-tion=0. 62). Similarly, there was no significant interaction between body silhouette trajectories and age at inclusion (p=0. 83). Hence, body silhouettes trajectories were described without stratification by gender or age. The reliability of the obtained trajectories was further tested using the kml package of R software. This method is based on an implementation of the k-means clustering algorithm adapted for longitudinal data. 31 According to quality criteria (Calinski and Harabasz, Ray and Turi and Davies and Bouldin),  31  the optimal number of trajectories was five. Using this approach, we found very similar body silhouette trajectories as the previous ones (online supplementary figure  1 ).
To minimise residual confounding by SDB, we then adjusted the model on loud snoring and then on the presence of a plausible SDB (missing in 538 subjects). To account for missing covariates, we reran the main analysis after using multiple imputations by chained equation. 32 inally, to test for an association with the severity of EDS, we considered moderate EDS (ESS between 11 and 14) and severe EDS (ESS ≥16), and performed multinomial logistic regression. All analyses were two sided and we considered a p<0. 05 as statistically significant. Statistical analyses were performed with R V. 3. 1. 3 (www. r-project. org) and SAS V. 9. 3.
They first revisited  Waugh and Norman (1965) 's data which were collected in a probe-digit experiment meant for weighting the respective effects of decay and interference. Participants were presented with a list of digits for study, followed by a probe digit which indicated that the memoranda following the first occurrence of the probe had to be recalled. This experiment was designed to measure the recall of digits as a function of the duration and number of memoranda following their presentation. Since there was a large effect of the number of interfering items and no effect of the presentation rate, the authors concluded that the main source of forgetting was interference. Altmann and Schunn (2012)  first showed that the interaction, which was neglected by Waugh and Norman, appeared to be highly significant, which is in favor of a relationship between decay and interference.
Cross-Domain Impairment of Memory by Processing (B5) As just discussed, memory is impaired when memoranda and distractors belong to the same content domain. However, findings B5 say that memory is also impaired, albeit slightly, when memoranda and distractors belong to different domains. Only the data with no memoranda-distractor overlap (MDO = 0) were then considered. Figure  10  shows that even if memoranda and distractors belong to different domains, distractors impair memory. This effect of the number of distractors appears dependent on the cognitive load, as we discussed earlier. Indeed, the effect is stronger for higher cognitive load values as already shown regarding the B2 benchmark. The classical pattern observed in TBRS * by  Oberauer and Lewandowsky (2011)  is then replicated in TBRS * -I.
Objects refer in COSMO to a range of possible meanings, conflating different levels of analysis (from words up to concepts and down to phonological units). In this paper, objects will only refer to phonological entities. For this designation task, the speaker produces a motor gesture M resulting in a sound S transferred by the environment to the listener, and enabling the listener to decode the object as O L (L for "listener"). The speaker-lis- tener interaction may be completed by an accompanying communicative action, providing a basis for reference  (Moulin-Frier et al. , 2015) : this is achieved in COSMO by a communication Boolean variable C so that = C True if and only if = O O S L. COSMO is based on an internalization hypothesis according to which the whole communication chain would be internalized in the brain of each agent (Fig.
When producing speech in noisy backgrounds talkers reflexively adapt their speaking style in ways that increase speech-in-noise intelligibility. This adaptation, known as the Lombard effect, is likely to have an adverse effect on the performance of automatic speech recognition systems that have not been designed to anticipate it. However, previous studies of this impact have used very small amounts of data and recognition systems that lack modern adaptation strategies. This paper aims to rectify this by using a new audio-visual Lombard corpus containing speech from 54 different speakerssignificantly larger than any previously availableand modern state-of-the-art speech recognition techniques. The paper is organised as three speech-in-noise recognition studies. The first examines the case in which a system is presented with Lombard speech having been exclusively trained on normal speech.
Materials: the Lombard Grid corpus Speech materials have been taken from the Audio-Visual Lombard Grid corpus 1   (Alghamdi et al. , 2018). Essential details for the data collection are repeated here for the sake of completeness. Speech materials were collected from 54 paid adult volunteers (24 male, 30 female). All volunteers were native English speakers with no self-reported hearing problems. Each stimulus consisted of a six-word sentence such as 'place blue at A 2 please' following the Grid corpus sentence syntax  (Cooke et al. , 2006) : < command: 4 > < colour: 4 > < preposition: 4 > < letter: 25 > < digit: 10 > < adverb: 4 > , where the number of choices for each keyword is indicated in the angle brackets (and there are 25 letters since the multisyllabic letter 'W is not included). There are 64,000 possible unique sentences with this structure.
Methods Training and testing data have been constructed by artificially adding speech shaped noise to the Lombard corpus utterances. Noise levels have been chosen so that the non-Lombard utterances have SNRs ranging from -12 dB to 0 dB in steps of 3 dB. This range was chosen to ensure coverage of noise levels that were free from performance floor and ceiling effectsit also spans the -9 dB SNR used in the Lombard Grid sentence perception studies of  Lu and Cooke (2008). Note that because the Lombard utterances have greater energy, for a given noise level, they will have a significantly higher SNR than the non-Lombard mixtures. This energy difference is the biggest part of the mismatch. In order to measure how much of the mismatch effect is due to this alone, a further set of 'compensated' Lombard (CL) noisy utterances are generated in which the Lombard utterances are normalised to the same normalisation energy as the non-Lombard utterances before adding the noise, i.
, 2017)  and the particular representation described here has been used to form the basis of successful models of speech intelligibility in noise  (Cooke, 2006). In all studies ASR systems have been trained using the Kaldi toolkit  (Povey et al. , 2011). The ASR is performed with a typical GMM-HMM setup. Each feature frame is concatenated with 3 neighbours from either side. The dimensionality is then reduced to 40 by means of a Linear Discriminative Analysis (LDA) transform. The resulting feature vectors are mapped to clusters of tied context-dependent sub-phonetic triphone states using Gaussian mixture models. Following  Young et al. (1994)  the states are tied using decision trees with a maximum of 2500 clusters and 15,000 Gaussian components. During decoding the language model assigns a uniform probability distribution among all possible Grid sentences, while at training time the language model assigns all the probability to the uttered Grid sentence, effectively performing a forced alignment.
In order to remove the effects of dataset mismatch and maintain a balance between speaking styles only speech data from the aforementioned Lombard Grid Corpus was used for training and testing the ASR systems. A multispeaker setup was chosen over training speaker-dependent models. The use of SAT and fMLLR allowed us to maximise the data available for training whilst increasing the specificity of the models to each speaker. Furthermore the scenario is common in many existing speech recognition tasks and applications. Due to the relatively small amounts of speech data, a leave-one-out style of training and testing is employed: 50 separate cuts of the data are employed, in which one Lombard/non-Lombard utterance pair from each of the 54 speakers is used to define a 54 utterance Lombard and non-Lombard test set which is evaluated against a model trained on the remaining 54 × 49 non-Lombard utterances.
(  2007 ) and  Davis et al. (2006) ). This lack of study is particularly true for robust ASR where the non-availability of sufficient Lombard-style training data has been a serious obstacle. Instead, ASR studies have taken databases recorded in clean conditions (such as the AV Grid corpus  (Cooke et al. , 2006) ) and artificially added noise. The one existing work that has examined audio-visual Lombard ASR has employed only 7 speakers, only 3 of which read full sentences  (Heracleous et al. , 2013). The continued neglect of Lombard visual speech in audio-visual ASR studies is particularly troublesome given that visual speech features are most likely to be useful to ASR in the low SNR situations that induce Lombard effects. In this study we repeat the mismatched and matched recognition studies of the previous sections but this time using the visual component of the AV Lombard Grid corpus.
5-mm of anterior and posterior slices were quantified. In each series, three sections separated by 80 µm were processed for BrdU immunoperoxidase. The DG outline was delimited in the same way. Five sections separated by 800 µm were processed for BrdU immunoperoxidase. For both SVZ and DG no significant differences were detected between the anterior and the posterior labeling (data not shown), therefore both series of data were pooled. To count DCX-positive cells and assess their distribution, hypothalamic frontal sections were analyzed using a Zeiss Axioscop 2 microscope equipped with a motorized X-Y-sensitive stage and a fluorescent lamp under a magnification of 109 coupled to a video CDD camera connected to a computerized image analysis system (Explora Nova, La Rochelle, France). Images were acquired using Mercator software (Explora Nova, La Rochelle, France) by applying the same contrast and exposition time for acquisition to compare labeled series accuratly.
Blots were blocked with Tris-buffered saline buffer supplemented with 0. 1% Tween 20 and 5% milk for 30 min at room temperature and membranes were then incubated overnight at 4 °C with specific rabbit antibodies against cyclin D1 (Santa Cruz Biotechnology, Texas, USA) or mouse antibodies against vinculin used as an internal standard (Sigma, St. Louis, MO, USA) at 1/1,000 final dilution. Blots were washed several times and incubated at room temperature for 1h30 with a HRP-conjugated anti-rabbit or anti-mouse IgG (dilution 1/5,000). The signal was detected with an ECL chemiluminescence kit using a G:Box SynGene apparatus (Ozyme) with GeneSnap software (release 4. 01. 02). The results are expressed as the signal intensity in arbitrary units after normalizing with the presence of vinculin. No western blot analysis could be performed with the ORP samples because of technical problems (frozen samples were accidentally thawed).
Statistical analyses. Normal distribution and equal variance assumptions were tested using the Shapiro-Wilk normality and Bartlett's tests, respectively. Multivariable datasets were analyzed using ANOVA, followed by a Bonferroni's multiple comparison test to produce multiplicity-adjusted p values for pairwise comparisons. Significance was defined as a p value of 0. 05 or smaller. Single variable pairwise comparisons were analyzed using a Student's t test.
Acknowledgements This work was funded by the  French National Research Agency (Agence Nationale pour la Recherche: SeasoNRG   ANR-09-JCJC-0049-01  and HypNeurogen  ANR-16-CE37-0006-01 ). L. Butruille is a Ph. D. student supported by the  Région Centre. The authors wish to thank the experimental unit PAO No. 1297  ( EU0028 ;  INRA Val de Loire ) for animal care and the  INRA  PRC hormonal assay platform for progesterone assays.
Participants Eighteen healthy adults (average age: 24; 6 males; 14 right-handed) with no history of neurological, psychiatric, or visual/hearing impairments as indicated by self-report participated in the experiment. Participants gave written informed consent and were paid for participation. Ethical approval was granted by the ethics committee of National Taiwan Normal University (Taiwan) and the University of Jyväskylä (Finland). Four participants were excluded from data analysis for excessive measurement noise, leaving fourteen participants in the final sample (average age 24; 3 males; 12 right-handed).
Stimuli Sinusoidal tones with a loudness of 80 phons (i. e. 80 dB for tones of 1000 Hz) were generated using Matlab. The duration of each tone was 50 ms (including 5 ms rise/fall times). The frequency of each tone was within the range of 261. 626 -493. 883 Hz, matching the absolute frequency of a series of seven natural keys on a modern piano (i. e. , C4 D4 E4 F4 G4 A4 B4). A total of 90 pairs of tone quartets (consisting of three prime tones and one probe tone) were created. Each pair of tone quartet was identical in the prime tones but different in the probe tone in terms of frequency (e. g. , F4-E4-G4-A4 and F4-E4-G4-D4). The frequency of the prime tones was determined by a random sampling without replacement, with the exception of any continuously rising or falling sequence to avoid the step inertia expectation (i.
Each tone was separated by a 500 ms stimulus onset asynchrony (SOA). 10% of the probe tones were of attenuated loudness by 20 dB. Participants were required to press a key when they detected a softer probe tone as soon as possible to maintain their attention. The offset of the probe tone was followed by a jittered inter-trial interval (ITI) of 700-800 ms. There was no separation between cycles distinct from the ITI. A fixation cross remained on the screen for the duration of the block. The whole experiment took around 42 minutes (i. e. , 900 trials x 2800 ms). Offline, head movements were corrected and external noise sources were attenuated using the temporal extension of the source subspace separation algorithm  (Taulu et al. , 2005)  in the MaxFilter program (Elekta Neuromag, Finland). After the initial head movement correction, the data was analysed using BrainStorm 3.
Acknowledgement This work was supported by  Taiwan Ministry of Science and Technology  (grant number  105-2410-H-003-145-MY3 ) to YFH and  Department of Psychology at the University of Jyväskylä  and  Academy of Finland  (profiling action "Multilete" # 292466 ) to JAH. We thank  Mr. Lauri Kantola  for assistance with MEG data collection.
In total, 18 complete sets of data were collected and were included in the current analysis. Two couples did not complete all the questionnaires at the end of the program by lack of time, one couple attended another group more adapted to their child whom had a higher level of language, three fathers dropped out of the group for reasons related to their work, while their partner continued to participate in the PT, and one of the mother who continued without her partner did not complete all the questionnaires. The participating parents ranged from 26 to 55 years old with a mean of 35 years (SD = 7. 2) and represented a wide range of social and cultural backgrounds. None of them had participated in any formalized parent training programs. All participating children were 3 to 5 years old with a mean of 3.
Social validity Descriptive data of social validity measures are summarized in Table  III. In pretreatment, all parents assessed the objectives targeted by the program as important or very important. They requested priority information on interventions to improve their child functioning. With a mean total score of 39. 39/45 on the TEI-SF, parents also considered the strategies learned during the program as acceptable to use with their children. More precisely, all parents had a total score above 27 which is the cut off for moderate acceptability. Parents' level of satisfaction measured by the TAI at the end of the program was also high: the mean total score is 40. 89/50. Similarly to the score of moderate acceptability in the TEI-SF  (Kelley et al. , 1989) , a moderate score of total satisfaction was calculated by adding a midpoint score of 3 on each item of the TAI.
Objective: The main objective of this study was to validate the French version of the WART. Methods: Questionnaires were proposed to voluntary French workers using the WittyFit software. There were no exclusion criteria. The questionnaire was administered anonymously for initial validity testing and readministered one week later for test-retest reliability. We also assessed the workers' sociodemographic characteristics, as well as other measurements for external validity, such as stress, well-being, and coaddictions to tobacco, alcohol, and cannabis. Several psychometric properties of the French-WART were explored: acceptability, reliability (internal consistency [Cronbach alpha coefficient] and reproducibility [Lin concordance coefficient]), construct validity (correlation coefficients and principal component analysis), and external validity (correlation coefficients).
Recruitment Questionnaires were proposed to voluntary French workers using the WittyFit software  [25]. WittyFit is a Web platform that aims to improve the well-being at work, with a public-private partnership with the University Hospital of Clermont-Ferrand. Workers using WittyFit answer-validated questionnaires on behavioral data for baseline health profiling. The concept of WittyFit is to provide individualized feedback based on evidence-based medicine, with an aim to support behavioral change using a formal evaluation of changes in knowledge, practices, and health outcomes over time. The database is implemented from a human resource-generated number, which is then automatically converted into another number in the WittyFit database. Data provided by employers (such as from the professional roles or the occupational sector) are automatically associated with the human resource-generated number.
All data are anonymous, and the name of the employee is never entered into the database. The study was approved by the National Commission for Data Protection and Liberties and by the South-East VI Ethics Committee (ClinicalTrials. gov NCT number NCT02596737). There were no exclusion criteria. The WittyFit users were informed of a forthcoming questionnaire validation study through this platform explaining the purpose of the study and the need to complete the questionnaire twice (test and retest, 1 week later).
Statistical Analysis The number of subjects required were determined in advance by following recommendations  [32]  and in accordance with our recruitment abilities. In this context, a complement of at least 120 participants appeared to be relevant for the test and 60 for the retest. Statistical analysis was carried out using the Stata software version 13 (StataCorp). Qualitative data were described in size and associated frequencies, and the data were compared between groups-those who only completed the questionnaire once (test) and those who completed the survey twice (test and retest) -with the chi-square test or with the Fisher exact test. Quantitative data, expressed by the mean (SD) or the median (interquartile ranges) regarding the statistical distribution (the Shapiro-Wilk test), were compared between groups with the Student t test (or an analysis of variance [ANOVA]) or Mann-Whitney U test or the Kruskal-Wallis test, if the t test's conditions were not respected (normality and homoscedasticity considered by the Bartlett test) for the quantitative variables.
When appropriate (P<. 05), a post hoc test for multiple comparison was deemed, namely, the Tukey-Kramer postANOVA test and Dunn test after the Kruskal-Wallis test. The comparisons between the groups for category parameters were achieved with the chi-square test or with the Fisher exact test. The difference was defined as statistically significant when the level of significance (P) was less than. 05 (alpha risk=5%). The psychometric properties of the WART were explored. We assessed the acceptability based on the calculation of missing data for each item and the dimension of the WART-data quality was deemed acceptable if less than 5% of data were missing. The accepted maximum for floor and ceiling effects was 15%  [32]. The reliability of the French version was evaluated according to two criteria: (1) internal consistency based on the calculation of the Cronbach alpha coefficient (desirable values higher than.
The chamber was connected to a data acquisition system (Emka Technologies) that measured flow and pressure changes within the chamber using Iox2 software. Data were sampled at 1 kHz. Recordings were analyzed offline using PClamp10 software (Molecular Devices). Breathing frequency was calculated on a breathto-breath basis. Interruptions in the breathing rhythm were considered as apneas when at least 1. 5 ongoing cycles were skipped. Because of the small size of animals at P0 and their very limited respiratory volumes, to avoid obtaining erroneous measurements we did not analyze other classically tested breathing parameters such as tidal volume, ventilation, and the durations of inspiration and expiration.
Electrophysiological recordings of neuronal activity With pontomedullary and medullary preparations, the activity of the phrenic nerve ventral root (C4) or that of the hypoglossal root (XII) was recorded using a suction electrode fabricated from glass tubing broken at the tip to match the diameter of the root in question. In transverse brainstem slices, preBötC population activity was recorded using a glass macropipette positioned at the surface of the slice in the region containing the preBötC respiratory network (in the proximity of the nucleus ambiguus). The recording pipette was filled with aCSF and connected through a silver wire to a high-gain amplifier (AM Systems). Signals were filtered (bandwidth 3 Hz to 3 kHz), rectified, integrated (time constant 100 ms; Neurolog, Digitimer), recorded, and analyzed offline on a computer through a Digidata 1440 interface and PClamp10 software (Molecular Devices).