dataesr/scientific-paragraphs-categorization huggingface dataset:
Interactions of the hCBP full length protein with the WT and AD1-ACTR analogues were analyzed in the manner of dose response using twofold dilution series of hCBP ranging from 200 to 0. 75 nM. The association and dissociation phase were 100 s and the analyte flow rate 40 μl/min. For regeneration, a solution of 6 M guanidine-HCl, 250 mM NaOH was injected into all channels at 5 µL/min for 60 sec. After subtracting the reference and buffer signal, the data were fit to a steady state binding model to define the apparent KD. Equilibrium signals were extracted from experimental SPR data for both systems and subsequently fitted with a 1:1 binding model. Since the data recorded for WT ACTR / hCBP interaction are so far from saturation, the fitting has been done in two steps: a first one by fitting the equilibrium data for the ACTR doubly methylated variant, leading, among others, to the maximum capacity Rmax value; then a second step in which the previous Rmax value has been used as forced parameter into the fit of the wild-type AD1-ACTR data, assuming that the saturation level is the same for both the wild type and the doubly methylated analogue (Supplementary Fig.
fluorescein labeled AD1-ACTR (WT and [1055meLeu;1076meLeu] variant) was diluted at 5 nM in the assay buffer (25 mM Hepes pH 7. 5, 150 mM NaCl, 1 mM TCEP, 0. 05% Tween-20) and mixed with increasing concentration of hCBP (0. 03-470 nM). The triplicates of the mixtures were transferred into 384 well black microplate (PS, F-bottom; Greiner Bio-one) and let incubate for 10 min at 25 °C in the dark. The FP was recorded by PHERAstar Plus (BMG LABTECH) at 25 °C, using excitation and emission filters of 485 and 520 nm, respectively. Graphpad Prism 8 software was used to calculate the dissociation constant (KD) by fitting a curve with the one site binding model (Supplementary Fig. 21). Supplementary Fig. 18(consists of 6 panels on pp. 34-38): Surface plasmon resonance binding data for WT AD1-ACTR, [1055meLeu]AD1-ACTR, [1076meLeu]AD1-ACTR and [1055meLeu;1076meLeu] AD1-ACTR at 20 °C (293 K) (curves in black correspond to fitting to 1:1 association model).
the  Swiss Light Source synchrotron ,  P. Scherrer Institute , We thank  V. Olieric  and  C. -Y. Huang  for their help on the beamline. We also thank  IGBMC  staff members  P. Poussin-Courmontagne ,  A. McEwen  and  C. Birck  from structural and biophysics platforms and to  Prof. S. Riniker  from the  ETH Zurich  for providing CPU time. This work has been funded by the  European Research Council  ( ERC-2016-StG , grant number  715062-HiChemSynPro ), the  CNRS , the  INSERM , the  Université de Strasbourg  (IDEX program  R701/W15RPE19 ), the  Région Alsace  and the  Hôpital Civil de Strasbourg. The authors acknowledge the support and the use of resources of the  French Infrastructure for Integrated Structural Biology FRISBI   ANR-10-INBS-05  and of Instruct-ERIC.
PATIENTS AND METHODS This prospective study included patients diagnosed with BC and treated at the Aristide Le Dantec UHC in Dakar, Senegal. Inclusion criteria included histologically or cytologically confirmed BC and indication for chemotherapy as initial treatment. Patients could be included regardless of disease stage, age, or Eastern Cooperative Oncology Group status. All patients provided oral informed consent. The study was approved by a local ethics committee. A structured questionnaire was used to collect clinical, sociodemographic, and QoL data, and was administered orally by paramedical staff to all patients. QoL was assessed using the FACT-B questionnaire after validated translation into Wolof following Functional Assessment of Chronic Illness Therapy 5 recommendations (Data Supplement), which ensured the validity of the Wolof version of the FACT-B questionnaire.
TOI aggregate scores have been used for other cancer types and are sensitive indicators of outcome. 6, 7 FACT-B is generally a self-administered questionnaire, but ours was interviewer administered (paramedical staff only) because of literacy issues. Data were collected at three different times: the initial consultation when chemotherapy was prescribed, then 3 months and 6 months after the start of systemic therapy. Standard protocol in the Le Dantec center was sequential neoadjuvant chemotherapy with four cycles of anthracyclinebased regimens followed by four cycles of taxanes. For a metastatic disease, first-line treatment was anthracyclinebased chemotherapy (six cycles) followed by second-line taxanes in cases of disease progression (six cycles). Adverse events (AEs) were evaluated on a grading scale of 0 to 5 using the Common Terminology Criteria for Adverse Events, version 5.
0. Patient characteristics were summarized using median and interquartile ranges (IQRs) for continuous variables, and numbers and percentages for categorical variables. Many patients were lost to follow-up, and exploratory analyses were consequently performed to assess the types of missing data before additional investigation. Little's Missing Completely at Random (MCAR) test was performed using the BaylorEdPsych package, version 0. 5, in R (https://cran. r-project. org/web/packages/BaylorEdPsych/index. html). The following candidate variables were included: age and FACT-B total score at baseline, 3 months, and 6 months. In addition, the association between FACT-B total scores at baseline and missing values of FACT-B total scores at 3 and 6 months were assessed using a Student t test. A linear mixed model was used with QoL score as a dependent variable to assess the changes in QoL over time.
QoL Data Only patients with BC whose native language is Wolof were assessable for QoL. The numbers of patients that filled out the FACT-B questionnaire were 96, 68, and 28, at baseline, 3 months, and 6 months, respectively (Fig 1   4 ). However, TOI scores did not significantly change over time (β = -0. 23; 95% CI, -0. 93 to 0. 50; P =. 53). There was a clinical difference of 8. 7 points between the median FACT-B score at baseline and at 6 months. At 6 months, 10 patients (37%) had clinically significant improvements (. 7) in FACT-B total scores compared with baseline. Only five patients (18. 5%) had clinically significant improvements (. 5) in the TOI scores at 6 months compared with baseline. Seven patients (26%) and 12 patients (44%) had clinically significant decreases in FACT-B total and TOI scores, respectively, between baseline and 6 months.
MATERIAL AND METHODS The first 100 patients were included in a prospective, non-randomized study of patients undergoing day-case SG. The study was part of a local research protocol registered as "Feasibility of Laparoscopic Sleeve Gastrectomy in Day-Case Surgery (GASTRAMBU)" (ClinicalTrials. gov identifier: NCT01513005)  [4]. This study was approved by the local institutional review board (Comité de Protection des Personnes Nord Ouest II). Data concerning the other 150 patients were prospectively registered in our database. At a preoperative consultation, patients were given a study information sheet and a drug prescription for the days after surgery. The study information sheet was a document summarizing the information delivered orally. It explained the particularity of SG performed as DCS compared to conventional hospitalization (clinical pathway).
Economic assessment All direct costs were calculated on an individual basis. Economic assessment was performed according to French guidelines evaluating direct medical costs over a 3-month period starting from the SG procedure. Direct medical costs were evaluated from a societal perspective (national health insurance). Indirect costs were not calculated as part of the study design because of the lack of comprehensive data. Costs were not discounted and were expressed in Euros. Data included hospitalization and rehospitalization costs (according to the CCAM and GHM codes transmitted for hospital funding) and were extracted from the patient's medical records. Scheduled consultation were included in hospitalization cost. Scheduled consultation on POD4 (with inclusion of laboratory assessment) were also included specifically on hospitalization cost for patients undergoing SG as DCS.
Statistical analysis Between-group comparisons of quantitative variables were performed with a t-test for paired series, whereas between-group comparisons of qualitative variables (including the primary endpoint) were performed with a McNemar's Chi-square test. Results are expressed as mean ± standard deviation and range (for quantitative variables) or number and percentage (for qualitative variables). The limit of statistical significance was p ≤ 0. 05. All statistical analyses were performed with SAS software (version 9. 2, SAS Institute, Cary, NC, USA).
Case series are necessary to demonstrate the possibility of performing these types of procedures as DCS. Morton et al  [31]  reported on a large prospective clinical database of patients undergoing RYGB, including 507 patients as DCS. In their series, patients with DCS had a higher 30-day readmission rate and a 13-fold increased risk of death (0. 8%) compared to the reference length of stay of two days. The problem with these series is the number of patients undergoing RYGB as DCS (n=507) and that the number of centers performing these procedures as DCS is not specified. Inclusion and exclusion criteria are also lacking. This type of series perfectly illustrates that ambulatory bariatric surgery must be rigorously monitored to avoid increased morbidity and mortality. RYGB can probably be performed as DCS, but more rigorous criteria are required for this type of management.
In our previous series, patients with OSA, regardless of the grade, were excluded from DCS. Garofalo et al  [17]  includes patients with mild, moderate or severe OSA treated with CPAP. Based on their experience, a retrospective analysis of a large American database  [36]  and a retrospective review of our database of patients with OSA, patients with OSA adequately treated by CPAP are no longer excluded, as these patients do not present an increased risk of postoperative complications after SG. No published series have compared DCS to inpatient SG based on the same preoperative demographic data. For this reason, we performed a case-matched study by selecting patients in our inpatient group that could underwent DCS but were excluded because of social criteria of DCS. This selected population have no major other comorbidities (such as asthma, chronic obstructive pulmonary disease or others) in order to avoid possible bias in our results.
Most published series of DCS highlight the earlier return to work following DCS, but no data are currently available concerning SG as DCS. Thirdly, even if we are the only university hospital in our region and usually managed most of post-operative complications from different centre in our region, we cannot assure in 100% of cases that we were able to capture readmissions/rehospitalizations if patient went to outside hospitals or other centres, particularly in patients undergoing SG as inpatient. Fourth, the protocol surveillance of SG as DCS compared to conventional hospitalization is quite different, in particular concerning the scheduled consultation at POD 4 (not present in case of conventional hospitalization). At the time we started to perform GS as DCS, no series exist concerning outcomes of SG as DCS and we wanted to limit possible risk associated with DCS with such surgical procedure.
1 V, and the frequency measured by an oscilloscope is 50 HZ. For the THD of voltage, the output waveform is measured by power analyzer, and the THD rate is 2. 3%. The efficiency of inverter 1 can be measured with the input power of 52. 7 W, the RMSs of current and voltage on the load are measured with , and the efficiency is 92% in accordance with Equation  (8). * * U I o o U I η = (8) The adjustment rate of Inverter 1 in the load is expressed as follows: when 0 I A = , the output line voltage is 1 U o ; when 2 I A = , the output line voltage is 2 U o. The load ad- justment rate is 2 1 0. 25% 1 1 U U o o S l U o - = =. The relationship between current and voltage is displayed in Table  2 , and the image fitted using MATLAB data is presented in Fig. 20. With the same condition, when the RMS of the load line current I o varies from 1 A to 3 A, the output power of Inverters 1 and 2 can be automatically allocated within a specified range (ratio K alters 1:2 to 2:1).
The absolute difference between the converted current of the output lines of the two inverters is less than 0. 1 A. The experimental data show that, when the system runs at the parallel power supply, the RMS of the current is 3 A, and the frequency is 50 Hz. Parallel inverter 1 and normal inverter 2 adjust the load size. Accordingly, the RMS of the load line current is 3 A, and the RMS of the line voltage is 24. 1 V. Furthermore, the frequency measured by the digital oscilloscope is 50 Hz. The output power of inverters 1 and 2 is maintained at 1:1. The output power ratio is equal to the ratio of output current given two parallel power supplies. The two output currents of , and the line current difference between two inverters is less than 0. 05 A. The relationship between the three currents and voltage is summarized in Table  3.
Background: We assessed 2 investigational 11-and 12-valent vaccines, containing capsular polysaccharides of 10 serotypes as in the pneumococcal non-typeable Haemophilus influenzae protein D-conjugate vaccine (PHiD-CV) and CRM 197 -conjugated capsular polysaccharides of serotypes 19A (11-valent) or  19A and 6A (12-valent). Methods: In this phase II, partially-blind, multicentre study (NCT01204658), healthy infants were randomised (1:1:1:1) to receive 11vPHiD-CV, 12vPHiD-CV, PHiD-CV, or 13-valent CRM 197 -conjugate pneumococcal vaccine (PCV13), at 2, 3, and 4 (primary series), and 12-15 months of age (booster dose), co-administered with DTPa-HBV-IPV/Hib. Confirmatory objectives assessed non-inferiority of investigational vaccines to comparators (PHiD-CV for common serotypes; PCV13 for 19A and 6A), in terms of percentage of infants with pneumococcal antibody concentrations !0.
Study design and participants This was a phase II, randomised, partially-blind, multicentre study conducted in Czech Republic, Germany, Poland and Spain, between July 2012 and January 2014. Healthy infants 6-12 weeks of age who had not been previously vaccinated against S. pneumoniae and did not meet any of the exclusion criteria (Supplementary Material, Text S1) were enrolled in the study, after written informed consent was obtained from parents or legally acceptable representatives. Supplementary data associated with this article can be found, in the online version, at https://doi. org/10. 1016/j. vaccine. 2018. 07. 023. Infants were randomised (1:1:1:1) into 4 groups to receive 1 of the 2 investigational vaccines (11vPHiD-CV or 12vPHiD-CV), PHiD-CV, or PCV13, administered at approximately 2, 3, and 4 months (primary series) and 12-15 months of age (booster dose) (3 + 1 schedule).
Acknowledgements The authors thank the study participants and their parents. The authors would also like to acknowledge the assistance of the investigators, clinicians, study nurses and other staff members in conducting the trial. In addition, they would like to thank the serological laboratory teams of the GSK group of companies for their contribution to this study, in particular  Karine Muller  ( Keyrus Biopharma  c/o  GSK ) for statistical analysis,  Anca Farkas ,  Liliana Manciu  and  Domenica Majorino  ( XPE Pharma & Science c/o GSK ) for protocol and clinical report writing,  Inge Delmotte  (Synter-actHCR Benelux NV) and  Mercedes Lojo Suarez  for global study management. Authors would like to thank  Petronela M. Petrar  ( XPE Pharma & Science c/o GSK ) for medical writing support and  Ekaterina Ivanova  ( XPE Pharma & Science c/o GSK ) for manuscript coordination.
Study Population The trial protocol is available in Supplement 1. We assembled a cohort of all consecutive kidneys recovered for the purpose of transplantation from donors deceased from brain death or circulatory death between January 1, 2004, and December 31, 2014. We also examined outcomes for the recipients of kidney transplants from these donors in the United States and in France. In both countries, we excluded living donor kidney transplants, multiorgan transplant recipients, kidneys that were offered to transplant centers but were never recovered, and patients with missing data to calculate the KDRI score (eFigure 1A and B in Supplement 2).
21, 22  By law, data collection is provided by all organ procurement organizations and transplant centers in France. The University of Pennsylvania determined that the proposal met eligibility criteria for institutional review board review exemption because all data are anonymized and studies using the data do not require institutional review board approval. The study was conducted according to French law stating that research studies based on the CRISTAL national registry are part of transplant assessment activity and do not require institutional review board approval. Kidney allocation policies are described in detail in https://www. agence-biomedecine. fr/. 23.
Statistical Modeling of Kidney Allograft Discard Practice in Each Country We used US and French data to estimate changes in the number of kidneys transplanted and discarded in the United States where French organ acceptance practices applied to organs donated in the United States, and vice versa. The association between the (log-transformed) KDRI score and kidney allograft discard was assessed through logistic regression analyses. A score was generated using the regression coefficient of the model, and a probability of discard using this score was generated for each patient. Model calibration using the KDRI was assessed by graphical methods and discrimination by the receiver operating characteristic (ROC) curve and area under the curve (AUC; eMethods 1. 1. 1 in Supplement 2). The Monte-Carlo simulation method was used to estimate the number of kidneys that would have been discarded using the KDRI-driven kidney acceptance practice between countries.
Estimation of the Gain or Loss in Allograft Life-Years Based on Observed Survival Data Using actual survival data, we then quantified the change in the number of years of allograft life that would have been saved or lost under a redesigned allocation system (for example, if kidney acceptance practices were modified) based on the allograft acceptance patterns in the other country. This number corresponds to the survival time of the kidneys that would have been saved or lost by mimicking the kidney acceptance practices of the other country and using the mean survival time associated with those kidneys. We used STATA statistical software (version 14, STATA Corp) and R (version 3. 2. 1, R Foundation) for the descriptive and survival analyses. All statistical tests were 2-sided, and P values <.
Additionally, many organs, particularly those from older donors, will be assessed based on biopsy results and additional parameters, including flow and resistance when placed on pump devices. The value of biopsies and flow parameters remains controversial. 6 otably, biopsies are less frequently performed in Europe, and organ donors with comorbidities affecting kidney health, including diabetes and hypertension, are more likely to be accepted in Europe. The differences in the process and discard rate of potential donor kidneys between the United States and Europe are well illustrated by Aubert et al 7 in this issue of JAMA Internal Medicine. The authors analyzed data collected over a 10-year period (2004-2014) found in the French and US kidney transplant databases and conclude that (1) organ discard rates in the United States are significantly higher than in Related article page 1365.
gondii. Host genotype and spatial location through GPS referencing of all trapping localizations were investigated in relation to T. gondii infection in 12 sites of the city of Dakar and on Goree Island. In each sampled site, the occurrence of over-prevalence zones of T. gondii infection was investigated through Kulldorf's statistic using SaTScan software. For the sites where a possible over-prevalence zone was identified, mice family lines were inferred from Discriminant Analysis of Principal Components (DAPC). In 3 of the 4 identified possible over-prevalence zones, T. gondii infection was not confined to a single family line, which suggested no association between kinship and infection occurrence. This finding rather suggests an environmental source of infection for mice associated with localized putative foci of environmental contamination and supports an oral route of infection for mice from Dakar rather than a cycle based on vertical transmission.
The area within the circular window, centered on the centroid of each household, varied in size from zero to a maximum radius never including more than 50% of the total population within a given site. The SaTScan software tested for possible overprevalence zones within the variable window around the centroid of each household group. The number of Monte Carlo replications was set to 999, and over-prevalence zones with statistical significance of p <0. 05 were reported.
Genetic structure analysis Within each site where a spatial over-prevalence zone was identified, we investigated the possible occurrence of distinct genetic groups of mice using Discriminant Analysis on Principal Components (DAPC)  (Jombart et al. , 2010). DAPC was performed using the adegenet package  (Jombart, 2008)  for the R 3. 4. 0 software (R Development Core  Team, 2009). This Bayesian clustering method is not based on a predefined population genetics model and is thus free from Hardy-Weinberg equilibrium assumptions.
Data used The TB surveillance data used in this study were extracted from the National Health Information System (DHIS2), which contains a module for the collection and analysis of TB data. TB cases are collected and reported from the diagnostic and treatment centers available in all health districts. TB surveillance reports were collected quarterly and captured in the DHIS2 set up in 2016. Historical aggregate surveillance data (2009-2015) from the NTP have been imported into this system, and data entry continues at the national level on a quarterly basis. We have included all epidemiological surveillance data recorded in the National Surveillance System (DHIS2) from 2011 to 2018 that were validated and published by the NTP. Population estimates were obtained from the National Statistics Institute (NSI), which conducted a general population census in 2014 and projected the population for subsequent years to 2020.
Operational de nition of variables The indicators analyzed in this study are calculated from the data elements collected from the quarterly report forms lled in by the agents of the diagnostic and treatment centers. These indicators are consistent with the WHO revised TB reporting framework published in 2013  (10). We targeted two indicators, the TB case reporting indicator and the treatment outcome indicator as described below: Tuberculosis noti cation rate: number of reported TB cases per 100,000 population. This is based on reported TB cases that are either bacteriologically con rmed or clinically diagnosed. Therapeutic success rate: Percentage of reported TB patients who have been successfully treated. Ebola noti cation rate: number of reported Ebola cases per 10,000 population.
An adjusted F-value (10% suppression) is reported, and a p-value initiated is derived from it. This model has been adjusted while estimating the mean difference of dependent variables ( TB cases noti ed) between interrupted periods (EVD, 2014 to 2016) and uninterrupted periods (2011 to 2013 and 2017 to 2018), taking into account the lag of the dependent variable and any other covariate speci ed. The signi cance was de ned as a value of p less than 0. 05. The DHIS2, Excel, and R 3. 5. 1 software was used for data analysis.