dataesr/scientific-paragraphs-categorization huggingface dataset:
Statistical Analysis Comparative data analysis was conducted with Graphpad Prism 6 for Windows (Graphpad Software, San Diego, CA, USA). As the studied variables (average of immunoexpression rate of the pro-inflammatory cytokines: IL-1β, IL-6, and TNF-α) were quantitative, the normality of the data was tested by using Kolmogorov-Smirnov and Shapiro-Wilk tests, and by graphical analysis. Thus, Mann-Whitney U test was used for the two groups' comparisons (study group, elderly patients; control group, young/middle-aged) and between cyst and granuloma for each pro-inflammatory cytokine, whereas the Kruskal-Wallis test was applied for the comparisons among the three pro-inflammatory cytokines in each group (for cyst and granuloma). Descriptive data for variables were reported as mean ± standard deviation (SD).
Objective: Dentists need a high level of awareness to limit the spread of COVID-19 (Coronavirus  disease 2019). This study aimed to evaluate the level of awareness and attitude regarding the risk associated with dental procedures among dentists. Material and Methods: An online questionnaire was submitted to dentists between April-May 2020. The questionnaire form included questions related to demographic data, the transmission characterization of SARS-CoV-2, and treatment of COVID-19 patients. Data were analyzed using IBM SPSS V23 and chi-square test (p ≤ 0. 05). Results: A total of 3825 participants (29. 1± 7. 6 years) were included. In COVID-19, the riskiest dental branch in terms of the risk of contamination through saliva was considered to be Periodontics (32. 2%), while the least risky branch was Orthodontics (0.
Este estudo teve como objetivo avaliar o nível de consciência e atitude em relação ao risco associado aos procedimentos odontológicos entre os dentistas. Material e Métodos: Um questionário online foi submetido aos dentistas entre abril e maio de 2020. O formulário do questionário incluía questões relacionadas aos dados demográficos, à caracterização da transmissão da SARS-CoV-2 e ao tratamento de pacientes com COVID-19. Os dados foram analisados usando IBM SPSS V23 e teste do qui-quadrado (p ≤ 0,05). Resultados: Um total de 3825 participantes (29,1 ± 7,6 anos) foram incluídos. Na COVID-19, o ramo odontológico de maior risco em termos de risco de contaminação pela saliva foi considerado a Periodontia (32,2%), enquanto o ramo de menor risco foi a Ortodontia (0,2%). Os procedimentos odontológicos específicos considerados de alto risco de contaminação foram preparo dentário (69,4%), raspagem e alisamento radicular (63,5%), obturação (53,4%) e pulpectomia (40,5%).
Study sample The study sample consisted of dentistry students (year-5), dentists, and specialist dentists, in Turkey, regardless of the place of work. The electronic addresses of the samples were obtained from the Turkish Dental Association (20000 e-mails), and their presence was assessed by confirming their places of work and registration with this association. Within all samples, 10040 dentists/dentistry students were randomly chosen to participate in the present study. Each randomly selected participant was also contacted individually to make sure they were a dentistry student/dentist and were working in Turkey. An online questionnaire form was created using Google Forms for data collection, and this questionnaire was sent to the previously selected emails. To test the questionnaire's comprehensibility, a pilot study was conducted with 40 dentists who were randomly selected.
Data Several parameters were recorded to evaluate reproductive performance: the incidence of retained placenta (RP), pregnancy rate after surgery, calving interval (calving in the year nþ1, extracted from BDIVET, a French national database) and culling rate. RP was defined as the presence of foetal membranes in the uterus by visual or vaginal examination more than 24 h after calving  [25]. Pregnancy diagnosis was performed by ultrasound (after 30 days post-mating) or by transrectal palpation (after 60 days postmating). Parameters known to influence reproductive performance were also recorded: season of heifer birth (autumn, winter, spring), age and body condition score (BCS) at C-section, season of calving and surgery records (size of the uterine incision, length of surgery defined as the time from the start of the preparation of the animal for surgery -including premedication -to the end of the cutaneous suture, first uterine suture pattern: puncturing or inverting).
Statistical analyses RP and the first uterine suture pattern were defined as binary variables. Each remaining quantitative variable was transformed into a qualitative variable. Three classes of variable were created using arbitrarily thresholds in order to obtain a relatively balanced distribution of animals among the classes (Table  1 ). Data were entered in Microsoft Office Excel 2016 and imported into SAS® Studio 3. 8 (SAS® University Edition) and GraphPad Prism® software (version 9. 0. 0 for Windows, GraphPad Software, San Diego, California USA, www. graphpad. com).
Discussion The objective of this field trial was to evaluate the impact of pre-C-section administration of a NSAID (meloxicam), in pain and inflammation management, on the fertility of Charolais beef heifers. The effects of meloxicam administration preceding C-section were evaluated by comparison with a group of control animals that only received the local anesthesia. This study was conducted during the 2016 breeding season on Charolais heifers in the Burgundy region, one of the main breeding areas for this breed in France  [26]. Meloxicam and control groups showed similar results for parameters such as « heifer birth season», «age and body condition at C-section», and «C-section period» (Table  1 ). These results are consistent with the data collected across France for Charolais heifers during the same period.
Acknowledgements The authors would like to thank the  Boehringer Ingelheim Company , for making this study possible, as well as the members of the  GTV Bourgogne-Franche-Comt  e and the farmers involved for their participation and implication in this field study. The authors would also like to thank  Fanny Pilot-Stork  ( Ecole Nationale V et erinaire d'Alfort, France ) for her expertise on physiology of pain and its management.
Statistical Analysis The sample size was estimated based on the results of a pilot study on 14 horses in each group and according to similar studies  [21, 25, 26]. The expected mean differences between the overall score assigned in the two groups were assessed. A test power of 80% and a significance level of 5% were used. Given the possibility of potential dropouts, faced with different breeds and temperament interactions, a number equal to twice the calculated number was enrolled. The Shapiro-Wilk's normality test was performed to determine if the available data was well-modelled by a normal distribution and the homogeneity of variance was tested with the Fisher F test. A paired sample t-test was used to investigate the difference between the observations at T0 and T10. Afterwards, a two-way ANOVA with time and group as fixed effects was performed to analyse the parametric data, and Pearson's Chi-squared test to compare categorical data of sedation and induction scores.
Image reconstruction Images acquired using the multiphoton microscope contained both the SHG and TPF channels in the form of two singlechannel grey images. To view both channels simultaneously, false colouring was required. A composite SHG and TPF image was compiled using the FIJI version of ImageJ (Fiji is just ImageJ (http://fiji. sc/)). Sequential images along the axis from cortical bone toward the disc were stitched using GNU Image Manipulation Program (GIMP 2. 8. 18). Raw SHG and TPF images were not processed before image reconstruction.
Raman data analysis Single Raman spectra were plotted using Origin8 (OriginLab, Northampton, MA, USA). For mapping data analysis, the data were loaded into Matlab R2019a (The Mathworks Inc. , Natick, Massachussetts, USA) for pre-processing. The spectra were subjected to baseline correction using asymmetric least squares smoothing 17 (λ = 100, i = 10, p = 0. 001) and additional cosmic ray removal using a 3 × 3 window median filter. Following the pre-processing, spectral ratios were calculated for univariate analysis similarly to previous studies. 10, 18 The employment of normalised spectroscopic ratios is essential as the absolute values of spectral bands can be affected by scattering cross-section, sampling volume, orientation, absorption and instrument settings in each measurement. 19 e following ratios were investigated: • Mineral to Matrix Ratio (MMR) [959 cm -1 /(855 cm -1 + 877 cm -1 + 922 cm -1 )]: this characterises the mineral composition of the bone.
These measurements were performed as detailed by  Lebret et al. (2018). A third, consecutive transverse section of LM (cranial side, at least 10 cm long) was taken, aged for 3 days at 4 °C, vacuumpacked and stored at À20 °C. After 24 h thawing at 4 °C, standardized LM samples (8 Â 4 Â 5 cm) were weighed, vacuum-packed, heated in a steam oven (70 °C, 50 min), cooled at 4 °C and weighed to calculate cooking loss. From each sample, 15 meat sections were taken with a punch (12 mm internal diameter) parallel to the fiber axis to determine shear force (Warner-Bratzler cell, Instron testing machine, Instron, Guyancourt, France). Data were averaged, and shear force was expressed in N.
Statistical analyses Statistical Analysis System software (version 9. 4; SAS Institute, Cary, NC, USA) was used to analyze the data. The pig was considered as the statistical unit for all traits. First, data were analyzed using a PROC MIXED model with the season and farm as fixed effects to calculate residues. The normality of residues was checked (Kolmogorov-Smirnov, P ! 0. 05). When necessary, data were logtransformed and tested again to assess the normality of their residues. Then, raw or log-transformed data were analyzed via the PROC MIXED procedure with season, farm and genotype at SNPs as fixed effects (Supplementary material S1). Slaughter BW and time from exsanguination to muscle sampling were included in the model as a covariate for data analysis of carcass traits and pHi, respectively.
, 2020; Danicke et al. , 2002; Dänicke and Winkler, 2015; De Baere et al. , 2018; Devreese et al. , 2015; Grenier et al. , 2017; Guerre, 2015; Tardieu et al. , 2020 Tardieu et al. , , 2008)). So, a valid strategy to reduce the toxins in tissues would be the distribution of a mycotoxin-free feed a few days before the animals are slaughtered. However, to date no data are available on this subject. The purpose of the present work was thus to measure FB1 and α-ZOL in poultry liver several days after exposure to the contaminated diet was stopped. This study was conducted using a realistic level of exposure to naturally contaminated corn fed to turkeys and chickens over a period of 14 days. Mycotoxins in the liver were measured on day 0, corresponding to the last day the animals were fed the contaminated diet, and two and four days later, after the animals had been fed a mycotoxin-free diet.
Analytes were separated using an InfinityLab Poroshell 120 column (3. 0 × 50 mm, 2. 7 µm). Detection was conducted after positive electrospray ionization using the previously reported optimized multiple reaction monitoring conditions  (Tardieu et al. , 2020 (Tardieu et al. , , 2019)). For each precursor ion, the most abundant product ion was used for quantifier, and two different ions were used for qualifier except for the internal standards for which one qualifier was used. Chromatograms were analyzed using MassHunter quantitative analysis software from Agilent. Acceptability criteria of the analytes in liver were defined in paragraph 2. 6. When acceptability criteria were not met, results were discarded and samples were re-analysed. Samples with analyte concentrations 25% above the maximum limit validated were diluted prior to re-analysis.
9 and 5 ng/g, respectively. A liver:feed ratio was calculated by dividing the concentration of FB1 in the liver by the concentration of FB1 in the feed. The ratio was 0. 79 × 10 -3 in turkeys and 0. 77 × 10 -3 in chickens. Four days after consuming the control diet, the mean concentration of FB1 in liver was 4 and 2. 3 ng/g in turkeys and chickens, respectively. These concentrations corresponded to 81% and 46% of the concentration measured on day 0 in turkeys and chickens, respectively. Modeling the data in Figure  1  estimated the decrease in FB1 in liver to be linear in both species (P < 0. 01). mg/kg FB1+FB2 (FBZEN) for 14 days. Livers were analyzed on day 0 corresponding to the end of the exposure to the FBZEN diet, and on days 2 and 4 corresponding to 2 and 4 additional days of feeding the animals with a mycotoxin-free diet.
However, we observed a higher dispersion of LAB counts for the case farms. It was the only criterion where the source of liquid feed had an impact on counts (p < 0. 05; Figure  3 ). There were more lactic acid bacteria in sow liquid feed sampled in farrowing than in gestating facilities. The heterotrophic bacteria counts were also closed in both groups, and no statistically significant difference between the two groups was observed. Total coliforms counts were significantly higher on case farms (p < 0. 05). However, this difference was not observed for thermotolerant coliforms, although the dispersion of thermotolerant coliform counts is higher in case farms. For sulphite-reducing bacteria, the difference between the two groups was not F I G U R E 1 Loading plots of the principal component analysis (PCA) reported the results of the elaborations carried out with datasets.
coli  4  and Salmonella typhimurium 11 is well documented. It has been demonstrated that the sow is a source of piglets lactic acid flora. 4 In this study, the average lactic acid bacteria count in sow liquid feed was higher in control farms, however, this difference was not significant. Moreover, LAB counts were significantly higher in lactating than in the gestating liquid feed. The reason for this observation is unknown but we can hypothesise that Lactobacilli might be added as pro-biotics in lactating feeds for example. This data was not recorded during our study. The LAB:TColi ratio is proposed to characterise the balance between these two populations in liquid feed,  24  and to describe if this balance is favourable or not in gut microbiota. 4 A higher LAB:TColi ratio in faeces is usually associated with a bacterial flora that contributes to improved animal performance.
Methods (a) Stimuli We selected 82 vocalizations with NLP from a corpus of authentic non-verbal vocalizations compiled from online sources  [42]. All selected vocalizations were relatively short (M ± s. d. = 1 ± 0. 5 s) and free from background noise, and all contained perceptually salient and manually annotated NLP. Acoustically, the stimuli consisted of intense vocalizations (screams, yells, roars, groans, etc. ) and expressed various emotions such as anger, pain, fear, jubilation and surprise  [42]. Each of the 82 prototype vocalizations was resynthesized in four conditions (no NLP, amplitude modulation [AM], subharmonics and chaos), for a total of 4 × 82 or 328 stimuli. Highly accurate contours of fundamental frequency ( f 0 ) were manually extracted with a step of 10 ms. The sounds were resynthesized with R package soundgen  [41]  using the pitch contour and smoothed spectral envelope (formants) of the original recording, but with a fully controlled glottal excitation source.
This enabled us to create otherwise identical sounds with the controlled addition of amplitude modulation, subharmonics, chaos or without any NLP (figure  1 ). The timing and duration of NLP were matched to that of the original recording. The spectrotemporal characteristics (i. e. the frequency and depth of amplitude modulation and subharmonics, as well as the depth of chaos) were chosen randomly from the range of values previously observed to provide a good approximation of NLP in human non-verbal vocalizations  [33, 41, 46]. All audio stimuli and R code for their synthesis are available for download at http:// cogsci. se/publications. html.
(d) Data analysis Unaggregated, trial-level data from all three experiments were analysed using Bayesian multilevel models, fit with the R package brms  [47]  with default, mildly conservative priors; for data-heavy models, these priors improve model convergence without notably affecting posterior estimates. Posterior distributions of model parameters and fitted values were summarized by their medians and 95% credible intervals (CIs). We compared credible values of effect sizes: when the credible intervals on estimates are far from the null value (e. g. zero), this indicates a credible effect given the observed data, model structure and prior knowledge. Full details of data analysis, as well as R code, are available in the electronic supplementary material.
If we add the size exaggerating effect in agonistic interactions, it is easy to see how selection may favour anatomical structures and physiological mechanisms that render the vocal organ unstable and capable of supporting complex vibratory regimes such as subharmonics and chaos, as indeed observed in the vocalizations of a wide range of animals, from birds and frogs to dogs and whales  [17, 20, 21, 23, 24, 29, 31]. From the receivers' perspective, the ability of NLP to prevent habituation is presumably based on their unpredictable nature and is thus derived from attentional mechanisms, while the present findings indicate that their size exaggeration effect is mediated by a cross-modal correspondence between size and auditory frequency or pitch. An important task in unravelling the evolution of vocal communication will be to achieve a fuller understanding of the nature and origins of such cognitive mechanisms, which may ultimately explain many universal features found in the acoustic code of different species.
Experimental design To investigate the impact of ivermectin transfer between treated mares and their foal, we used fourteen Welsh pony mares and their foals. Pregnant Welsh pony mares were allocated to two 7 ha pastures in April 2019. Pasture allocation was balanced for the stallion they were mated with, and for the foreseen date of foaling. This latter parameter was considered to obtain similar foal parasite exposure across pastures. Foaling took place from May 25 to June 23 2019. Detailed metadata are provided in supplementary Table  1. Faecal egg count (FEC) was performed every month (from early June to late August) in the seven mare-foal pairs (supplementary Table  1 ) to quantify strongyle egg excretion. Foals were not sampled before they reached 14 days of age. For each pair, animals were placed in a paddock to collect fresh faecal material off the ground.
Blood samples were centrifuged at 1500 g and 4 °C for 10 min to harvest plasma. Both milk and plasma samples were cryopreserved at -80 °C until ivermectin concentration was subsequently measured. Ivermectin concentrations were determined by High-Performance Liquid Chromatography with fluorescence detection according to previously validated methods in plasma  (Alvinerie et al. , 1999)  and in milk  (Alvinerie et al. , 1993). Data were analyzed by a non-compartmental approach using the KineticaTm software (version 4. 2, innaPhase, Philadelphia, USA). Apparent and maximal concentration (Cmax) and time of Cmax (Tmax) were then determined. The partial area under the plasma concentration time curve (AUC) and the mean residence time (MRT) were calculated from 0 to 7 days by the linear trapezoidal rule.
Statistical analysis Statistical analysis on FEC data was implemented in R v4. 0. 2 (R Core Team, 2016). Treatment efficacy was assessed by FEC reduction in the treated group corrected for FEC trajectory in the control group  (Presidente, 1985)  : 100 × (1 - ) , where FEC14 and FEC0 correspond to group average FEC measured before and after treament respectively. This formula was applied to measure ivermectin efficacy in mares and in foals whose mares had been treated. Efficacy in foals was estimated from the only foals with patent strongyle infection (n = 5 in the mare treated group and 6 in the control group). Efficacy below 0% were censored to 0. Confidence intervals (95% CI) were estimated using the R-version of the eggCounts package v2. 3  (Wang et al. , 2018). In addition, to determine whether FEC reduction was significantly different between experimental groups, we modeled FEC data with a marginal modeling approach using the geeM package v.
0. 10. 1  (McDaniel et al. , 2013). The implemented model was: FECij ~ β0 + β1 x dayij + β2 x groupij + β3 x dayij x groupij, where FECij stands for the j th FEC record in individual i, with an auto-regressive correlation structure between FECij and FECij+1, β0 is the intercept, β1 to β3 are the regression coefficients describing the covariate effects (day, treatment group and their interaction). Because of the over-dispersed nature of FEC, a negative-binomial function was used as a link function between the linear combinations of covariates and observed FECSignificance of the interaction term (P-value < 0. 05) would indicate egg count reduction between groups. Data and R script used for this study are under the following repository: https://github. com/guiSalle/Ivermectin-in-lactating-ponies.
A multigene phylogeny based upon 6,933 bp encompassing 11 genes, further confirmed the closer relationship of G. ellingtonae to G. rostochiensis and the G. tabacum complex than to G. pallida  (Zasada et al. , 2015). To date, there are sequences for four populations of G. ellingtonae available in Genbank from the United States, Chile, and Argentina  (Handoo et al. , 2012; Lax et al. , 2014; Skantar et al. , 2011). This is just a handful of data compared to what is available for G. rostochiensis and G. pallida  (Subbotin et al. , 2020). To expand our knowledge of the biodiversity of G. ellingtonae and facilitate further work on Globodera biogeography additional molecular data is required. In this study, we performed whole genome shotgun (WGS) sequencing on G. ellingtonae populations collected from Chile.
Each sample was uniquely barcoded and multiplexed in equimolar concentrations prior to sequencing on the Illumina HiSeq 3000 platform. Paired-end 150 bp reads were obtained from the CGRB along with associated sequencing quality information. Raw sequence data is available for download from the Sequence Read Archive (SRA) under BioProject PRJNA748409. Visual inspection of sequencing quality reports resulted in the removal of one sample (Socaire B1) from additional analyses based on the overall poor sequencing quality metrics. The remaining samples were trimmed to remove bases with Phred quality scores < 20 and remove adapter sequences using bbduk (https://sourceforge. net/projects/bbmap/). A single-gene phylogeny was constructed for Heat Shock Protein 90 (HSP90) to facilitate comparison to other Globodera sequences available in Genbank.
A single 1402 bp HSP90 sequence from G. ellingtonae (MK105568. 1) was used as a reference to anchor the assembly of the locus from each sample using the software package SAUTE (Souvorov and Agarwala, 2021). Sequences from identified Globodera and Cactodera (outgroup) from PopSet 1780190675  (Skantar et al. , 2021)  were used for comparison, as were the partial HSP90 sequences obtained by Lax et al. (  2014 ) from a G. ellingtonae population collected in Argentina. All sequences were aligned using Muscle v3. 8. 31  (Edgar, 2004) , trimmed to the shortest sequence length (final alignment of 437 bp) and a maximum likelihood phylogenetic tree was constructed using FastTree v2. 1. 11 (Price et al. , 2010). The HSP90 locus could not be reliably reconstructed for three samples: Talabre D7, Socaire B7, and Socaire H6, therefore, these samples are not included in the HSP90 phylogenetic tree.