dataesr/scientific-paragraphs-categorization huggingface dataset:
Main findings Our pilot cluster randomised trial demonstrated the potential of active breaks to reduce MSD symptoms and eyestrain. The I-Preventive software program was shown to be particularly effective in the short term in its individualised and personalised form, allowing workers to focus on areas of their choice by offering exercises that are easy to perform at the workplace. However, despite this digital tool being easy to use, adherence decreased over time, so that this favourable impact was not maintained over the long term. Validated methods for the prevention of MSD Prevention of MSD should be based on an integrative approach combining ergonomics and physical activity interventions. 13 In ergonomics, no clear positive impact has been demonstrated by single intervention programmes, such as workstation adjustments (technical), rest breaks (organisational) or ergonomic training (behavioural) on work-related MSD.
31 The novelty of the I-Preventive strategy is its implementation of frequent short daily active breaks promoted by a software program. A novel digital tool for the prevention of MSD Computer usage and sedentary behaviour at the workplace has increased dramatically over the past decade. 32 ffice workers thus remain in the same posture for longer, accompanied by long periods of keyboard usage, which can cause and aggravate MSDs. Paradoxically, several software programs have been implemented to promote exercise at the workplace and reduce MSD. Despite the promotion of exercise through software, however, programs have been largely developed for chronic diseases like type 2 diabetes,  33  and these digital strategies were rarely implemented at the workplace for health outcomes in general  34  and especially not for preventing MSD.
Statistical analysis Continuous and categorical variables were expressed as number and percentage or as median and interquartile range, respectively. Comparisons were performed by nonparametric (Mann-Whitney) and chi-square tests as appropriate. In the matched-cohort population, the effect of the strategy of DC insertion (GWE vs. VPI) on colonization and on DC dysfunction was estimated with a marginal Cox model, controlling for differences between groups before DC insertion and at DC insertion, selected by stepwise analysis. The statistical unit was the DC. Statistical analyses were performed with SAS statistical software, version 9. 3 (SAS Institute Inc. , Cary, NC, USA) and R statistical software, version 2. 12. 1 (R Foundation for Statistical Computing, Vienna, Austria). A p value <0. 05 was considered significant.
Results of the matched-cohort analysis Of the 2172 DCs recorded in the ELVIS database and used for the intention-to-treat analysis, 272 were inserted by GWE in 205 patients. Of these, 178 could be matched with controls according to the matching criteria and were therefore used as cases. The 178 controls were identified from 150 DCs in 143 patients in the database (matching with replacement). The characteristics of the patients and DCs are given in Tables  1  and 2. In the GWE group, the reason for prior catheter removal was known in 107 cases, and the reason was dysfunction in 97 cases and suspected infection in 10 cases. In the VPI group, 48 DCs were replacement catheters. The reason for catheter removal was  known in only nine cases, and this was dysfunction in eight cases and suspected infection in the other.
Limitations Our work has certain limitations. First, the choice as to whether to perform a GWE or a VPI was at the discretion of the treating physician, and the reasons for the choice were not recorded in the ELVIS database. Thus, no specific adjustment could be performed to take into account these criteria. In our study, in accordance with recommended guidelines  [14] , GWE was rarely performed for replacement of a DC with suspected infection. Second, as a non-randomized study, it is potentially subject to bias in patient selection. However, the results were probably not affected because of the matchedcontrol approach, which balanced the main risk factors for DC colonization between both groups. Third, we cannot exclude the possibility that we failed to detect an increased risk in DC colonization after GWE because the study did not have sufficient power.
Acknowledgements This study was supported by Grants from the  French Ministry of Health  ( Programme Hospitalier de Recherche Clinique National 2008 "ELVIS" and Programme Hospitalier de Recherche Clinique Inter-régional 2009 "ESCAPE "). We thank  J. Watts  for assistance in preparing and reviewing the manuscript. We thank  Dr A. AitHssain  ( Medical-Intensive Care Unit, University Hospital, Clermont-Ferrand, France ),  Drs O. Martin ,  M. Cour  and  T. N. Phan  ( Medical-Intensive Care Unit, University Hospital, Lyon, France ),  Dr G. Hilbert  ( Medical-Intensive Care Unit, University Hospital, Bordeaux, France ),  Dr F. Zéni  ( Medical-Intensive Care Unit, University Hospital, Saint Etienne, France ),  Dr J. M. Constantin  ( Department of Anaesthesiology and Critical Care Medicine, University Hospital, Clermont-Ferrand, France ),  Dr M.
Information from company files, including for deaths, is near complete: The most recent published study of attrition from the GAZEL cohort found that after nearly 25 years only 2. 6% of the initial participants had dropped out of the study, and around three-quarters of the participants return the annual questionnaires each year. 9 The GAZEL cohort contains many participants who held manual occupations and have been exposed to strenuous and hazardous working conditions. We included only male cohort members in the sample (n=15 011 men). A further 25 participants were excluded because they lacked company records, and 174 participants had died by or at the age of 50 years. There were some missing data, as a result of non-response and survey attrition: 133 people lacked information on at least 1 of the physical occupational exposures and a further 1306 participants had missing data for health or chronic conditions, leaving a final sample of 13 393 men.
The Stochastic Population Analysis for Complex Events (SPACE) program in SAS V. 9. 4 was used to estimate multistate life table functions. 6 Multinomial logistic models were used to estimate transition probabilities; transition tables with agespecific predicted probabilities of transition between health states are presented in online supplementary tables S1 and S2. For estimates of health expectancies using self-rated health, 4 transitions could occur from 1 year to the next: healthy to unhealthy, unhealthy to healthy, healthy to dead, unhealthy to dead. Death was an absorbing state, while the other states were reversible. For estimates of health expectancies using chronic health conditions, only 3 transitions were possible as, by definition, recovery from chronic conditions was not possible.
Cohorts Unit, INSERM UMS 11 responsible for the GAZEL database management, particularly Sébastien Bonenfant for efficient preparation of the data, and the GAZEL cohort participants. Contributors All coauthors participated in the planning of the research, the interpretation of the data analysis, and reviewed and edited the final manuscript. LGP wrote the first manuscript draft, and LGP and JH performed the data analysis, with input from HSC.
Masker and target were 10-ms Gaussianshaped sinusoids with a bandwidth of approximately one critical band. The overall pattern of results is qualitatively similar to existing data for long maskers. To facilitate implementation in audio processing algorithms, a dataset provides the measured TF masking function. The second goal was to assess the potential effect of auditory efferents on TF masking using a modeling approach. The temporal window model of masking was used to predict present and existing data in two configurations: (1) with standard model parameters (i. e. without efferents), (  2 ) with cochlear gain reduction to simulate the activation of efferents. The ability of the model to predict the present data was quite good with the standard configuration but highly degraded with gain reduction.
In order to fill this gap, the present study reports experimental data on TF masking for Gabor atoms, namely 10-ms Gaussian-shaped sinusoids, that are well localized in the TF plane and approximate the auditory frequency resolution around 4 kHz. A modeling approach is also presented with the aim to assess the potential effect of auditory efferents on the spread of TF masking. Auditory masking has been the focus of many psychoacoustic studies over the last decades (for a review see e. g. [14] ). Auditory masking refers to the degradation in the audibility of a sound, the "target", by the presence of another sound, the "masker". This effect is quantified by measuring the detection threshold of the target in the presence and absence of the masker. The difference in thresholds (in dB) then corresponds to the "amount of masking".
g. [31] [32] [33] ), filter functions  [16, 34] , and masking patterns for various ΔT s  [18-20, 35, 36]. However, in the following we provide arguments for why these data may not suffice to estimate the TF spread of masking for the particular type of stimuli under consideration here, namely TF atoms well localized in the TF plane. PTCs and filter functions are measured for a fixed f T and variable f M. To obtain a PTC, L T is fixed at a low level and L M at threshold (i. e. when the target is just audible) is measured for each f M. To obtain a filter function, L M is fixed and L T at threshold is measured for each f M. Because PTCs and filter functions are assumed to measure the response of a single auditory filter centered at f T , these two types of spectral masking functions are commonly used as estimates of auditory frequency resolution (e.
Based on these considerations we concluded that the spread of TF masking for a well-localized signal can hardly be derived from existing data and has therefore to be measured. In this study, we collected masking data for 10-ms Gabor atoms to characterize TF masking for this particular class of stimuli that may be useful for audio signal processing applications. Gabor atoms have Gaussian shapes in both time and frequency and minimize the TF uncertainty principle  [1, 2]. Additionally, it has been suggested that Gaussian-shaped stimuli with an appropriate support in the TF domain excite a limited number of hypothesized TF observation windows of the auditory system compared to broadband and/or long stimuli  [50]. Using stimuli with a compact support in the time domain also has the potential advantage to avoid the influence of auditory efferents like the MOCR.
Methods Listeners Four normal-hearing listeners participated in the experiment. All had thresholds of 15 dB HL or lower for octave frequencies from 125 Hz to 8 kHz and had no indications of hearing disorders. Two of them (L2 and L3) were highly experienced in psychoacoustics tasks. All listeners were volunteer and gave informed consent before the experiment. They were informed on the procedure and were free to withdraw at any time. The consent was verbal because the study involved no procedures for which written consent is normally required: (1) the study presented no more than minimal risk to the listeners (headphone presentation at low SPLs), (2) the alteration of consent procedures would not have affected the listeners' rights, (3) the listeners were not deprived of any financial benefits because there was no commercial exploitation of the data, (4) there was sufficient protection of listeners' privacy; and (5) the confidentiality of the data was implicit as no personally identifiable information (such as names or addresses) of the listeners was collected.
The starting level of the target was about 10-15 dB above the expected threshold, as determined by practice trials. The target level varied adaptively by initial steps of 5 dB and of 2 dB following the second reversal. Twelve reversals were obtained. The threshold estimate was the target level averaged across the last 10 reversals. A threshold estimate was discarded when the standard deviation across these 10 reversals exceeded 5 dB. Before data collection, practice series were performed for a number of conditions until the threshold estimates became stable. Then, two threshold estimates were obtained for each condition. If the standard deviation of these two estimates exceeded 3 dB, up to four additional estimates were completed. The final threshold was the average across all estimates obtained after practice series (maximum = 6).
e. supposedly without any efferent effects like MOCR). Similarly, step 3 consisted in using the k value found in step 1 but applying a gain reduction of 15 dB to simulate the MOCR. The same approach was used in  [48]  and  [37]  to account for efferent effects in the DRNL filter and in the power-law model, respectively. The procedure was repeated for each model. Overall, a single value of k was used for the whole data set. Although the detection efficiency may vary between listeners, fixing k seems reasonable here because our goal was to simulate mean data. Model Parameters. A MATLAB implementation of the DRNL temporal window model provided by the first author in  [52]  was used. Noteworthy, the model version presented in  [52]  does not include the middle-ear filter. The middle-ear filter was added in  [63]  and was used in all simulations reported below.
Noteworthy, in  [75]  the spectral and temporal masking functions are combined using a power-law function. This approach is more consistent with auditory processing than the linear combination, but the temporal masking function in  [75]  does not include the effect of ΔF on the temporal decay of masking. Thus, it is also no satisfactory TF masking model. To obtain more accurate predictions of TF masking, audio applications might incorporate the present data, provided in S1 Dataset, for instance as a TF masking kernel (see e. g. [76, 77]  for applications of the present data to sparse representations of audio signals). Alternatively, the temporal window model of masking could be used so long as short maskers are considered (unless a time-dependent gain reduction stage is implemented). A weakness of the temporal window model for audio applications, though, is its rather high computational load, especially when off-frequency and off-time listening are allowed for.
Inclusion criteria and participating cohorts The 15 cohorts providing primary data included in this analysis participated in the European project Environmental Health Risks in European Birth Cohorts (ENRIECO, www. enrieco. org) [16]. To be included in the analysis the cohorts had to recruit the newborns during pregnancy or shortly after birth, have information of maternal and infant exposure to active and passive smoking, have data available on the development of wheeze before the age of 2 years and data on major potential confounders. The list of included cohorts is given in online supplementary table  S1. The cohorts commenced recruitment during 1990-2008 and each included between 330 and 14 057 newborns (online supplementary table S1). A total of 37 459 mother-child pairs were available from the birth cohorts, of which 27 993 had complete data on second-hand smoke (SHS) exposure and wheeze (table 1).
A comparison of subjects included and those excluded because of missing information on key passive smoking exposure or outcome variables is shown in online supplementary table  S2. Multiple imputation was used to replace missing values in covariates (up to 9% for some covariates) and to address the potential bias and loss of precision that could result from incomplete case analyses. We created 10 imputations, generating 10 complete datasets that we analysed following the standard combination rules for multiple imputations  [17]. The variables included as predictors were siblings, birthweight, gestational age, parental allergic status, parental education, sex of the child, damp and breastfeeding.
Definitions of exposure to active and passive smoking Primary individual data were collected that included information on active maternal smoking and passive smoking obtained from questionnaire data submitted by each cohort. Responses were harmonised so as to Based on the different possible combinations of exposure to tobacco smoke, eight exclusive exposure groups were created and each participant was assigned only to one of the eight possible combinations of exposure, as depicted in table 2. This full detailed categorisation was available for a total of 27 993 children.
Although we did not have the exact timing of postnatal passive smoke in relation to timing of wheezing symptoms during the first 2 years it seems very unlikely that parents would start smoking in front of their children after, rather than before their children had a wheezing episode. Our large sample size provided a robust dataset that permitted the investigation of the independent role of each window of exposure ( prenatal versus postnatal) and exposure type (active smoking versus passive) on the development of wheeze before the age of 2 years. Cohort-specific odds ratios and 95% confidence intervals and meta-analysis using random effects, adjusted for sex of the child, siblings, birthweight, parental atopic status and gestational age. main limitation of our study was that we relied on parental report for both the exposure and the outcome, which may be subject to underreporting, recall and report bias.
Supported by the  European Community 's  Seventh Framework Programme  ( FP7/2007-2013)  under grant agreement no  226285  and, in part, by a  Flight Attendant Medical Research Institute (FAMRI)  grant (clinical investigator award 072058). The data collection and study teams of all participating birth cohorts were funded by local and/or national research organisations. The  UK Medical Research Council  and the  Wellcome Trust  (grant  092731 ) and the  University of Bristol  provide core support for ALSPAC study. Funding information for this article has been deposited with FundRef.
Methods: Twenty-nine vine-workers voluntarily participated in this study. Twenty-two reported low intensity of low-back pain while seven were pain-free. PPTs were assessed among 14 anatomical locations in the lower back region. Three trials were performed on each location with an interval time of at least one minute. Reliability was assessed computing intraclass correlation coefficients (ICC), standard error of measurement (SEM) for all possible combinations between trials. Bland-Altman plots were also generated to assess potential bias in the dataset. Finally, a repeated measure analysis of variance (RM-ANOVA) with the number of trials used as within subject factor was performed on (1) PPT, (2) ICC and (3) SEM values. Results: ICC ranged from 0. 86 to 0. 99 for all anatomical locations and for all possible combinations between trials.
Experimental protocol The PPT measurements were performed during working hours in one session lasting approx. 30 min using a hand-held electronic algometer (Somedic Algometer type 2, Sollentuna, Sweden) with a 1 cm 2 wide rubber tip. PPTs were assessed over 14 anatomical locations in the low back region with 7 locations on each side of the lumbar spinal processes L1-L5. Each location was measured trice (Trial 1, Trial 2 and Trial 3) by a single rater with at least 1 min between two consecutive trials on the same location to avoid temporal sensitization  [41]. The algometer was calibrated prior to data collection. Pressure was applied at a constant slope of 30 kPa/s with the tip of the algometer perpendicular to the skin. The worker was lying comfortably in a prone position on a table and was asked to press a button that locks the algometer display when the feeling of pressure changed to pain.
MDC gives the minimum value for which a difference can be considered as "real". MDC was calculated with the formula: MDC ¼ SEM Â 1:96 Â ffiffi ffi 2 p Furthermore, Bland and Altman plots of the differences between trials against their mean and limits of agreements (LOA) were used to assess the magnitude of SDDiff n s disagreement between trials. A difference between trials outside the LOA can be considered as a real change  [46]. Additional analyses using gender and a median split for age, BMI and pain intensity were conducted for the PPTs from the overall low-back (mean PPTs of the 14 anatomical locations) to address the effects of modifier factors. A student t-test was then used to compare groups. All data analyses were performed with R 3. 0. 1 software. Results are presented as mean (SD) or (95 % confidence interval), unless otherwise indicated.
Acknowledgements The authors are grateful to the  Château Larose-Trintaudon (Saint-Laurent Médoc, France) , the  Château Pichon-Baron (Pauillac, France)  and all the vineyard workers for their active participation. This work is also part of a  larger pluri-disciplinary project called 'EWS' (Ergonomics at Work  and in Sports). EWS project has benefited from support from the  Blåtand French-Danish scientific cooperation program  ( Institut Français du Danemark ), the  Direction des Relations Territoriales et Internationales from Univ. Grenoble Alpes (France)  and  Aalborg University (Denmark). The authors would like to thank anonymous reviewers for helpful comments and suggestions.
Balance control in upright position has direct impact on shooting performance in various competitive activities like archery, rifle shooting, etc. Feet positions and global posture of the athlete change between each shooting activities. Information and short time feedback about the variation of the centre of mass of the athlete during the time before the shoot appears essential for learning and developing skills in shooting sports. In this aim, the purpose of the study was to explore the accuracy and reliability of a motion analysis system which uses the technology of inertial sensors (MVN Biomech system, Xsens). The MVN Biomech system is composed of 17 miniature inertial centrals attached to the full body. The validation procedure consisted in comparing the data of twenty subject's centre of mass directly extracted from the MVN Biomech system with those given by an optoelectronic system (Vicon) composed of 8 infrared camcorders.
For the seven past years, devices with small sensors have been increasingly used to measure human motion in sport. For example, Xsens proposes to measure specific human motion in sport training using 17 connected inertial sensors (MVN Biomech). Only two studies have explored the accuracy of MVN Biomech  [10, 14]. More data clearly needs to be collected from MVN Biomech to examine its accuracy. In this aim, the purpose of the study is to investigate the accuracy and reliability of MVN Biomech estimating centre of mass position during upright posture. Data of the MVN Biomech system (Xsens Technologies BV, Enschede, Nederlands) was compared with the reference device Vicon Motion system (Vicon Motion systems, Oxford, UK).
Method The experiment took place inside the laboratory of Superior School of Osteopathy Paris. Twenty healthy subjects (10 male and 10 female) voluntarily participated to this study. All subjects were asked to perform three quiet stances in natural position, arms along his body, looking forward, during thirty seconds followed by a vertical jump. Kinematic data were collected simultaneously with a MVN Biomech system and Vicon systems (fig. 1 ). At all, sixty upright postures were studied. The Moven system is composed of 17 miniature inertial centrals (nanotechnology inertial motion units, nIMU) attached to the body by straps. Each nIMU contains three gyroscopes, three accelerometers, three magnetometers in a 35 g box about the size of a match box. Each nIMU captures in real time the full 6 degrees of freedom of the body where it is fixed.