dataesr/scientific-paragraphs-categorization huggingface dataset:
4, which makes the control of forces f significantly easier. The calibration process is described in greater detail in Supplementary Note 1 and Supplementary Figure  1. Our SLM-control software has a response time of a few microseconds  56  , which permitted us to reliably automate drag-and-drop experiments in a feedback system. The position of all colloids is identified on-line by a peak detection algorithm. The centroid of a small box around the presumed location of the colloid is then calculated from the background subtracted image to refine the position estimate. The optical setup and the microfluidic chip have been described before  35, 57. In contrast to previous publications, we use a Mikrotron MC1362 with adjustable frame rate. The intervals in which measurements are conducted were chosen to be centred in the channel.
Acknowledgements We thank  S. M. Bezrukov  for stimulating discussions. The research leading to these results has received funding from the  European Unions   Horizon 2020 research and innovation program  under  European Training Network (ETN)  Grant No. 674979-NANOTRANS (J. G. ). M. R. -C. has received funding from the  European Unions Horizon 2020  research and innovation programme under the  Marie Skłodowska-Curie  grant agreement No  749944. J. G. acknowledges the support of the  Winton Programme for the Physics of Sustainability. U. F. K. acknowledges funding from an  ERC   Consolidator Grant  ( DesignerPores 647144 ). F. R. acknowledges support from the  Spanish Research Council  [ FIS2016-80458-P ];  Catalan Government [Icrea Academia.
Drugs were bath-applied through a peristaltic pump-driven perfusion system and a complete exchange of the recording chamber volume occurred in approximately 1 min. Neurons within DRN were visualized by infrared differential interference contrast (IR-DIC) video microscopy with a Newicon camera (C2400-07; Hamamatsu, Hamamatsu City, Japan) mounted on an upright microscope (Axioskop; Zeiss, Go ¨ttingen, Germany). Recordings were made using an EPC-10 amplifier (HEKA Elektronic, Lamberecht, Germany). Patch pipettes were prepared from thick-walled borosilicate glass on a P-97 Brown-Flaming electrode puller (Sutter Instruments, Novato, CA, USA). Data were analyzed using Patchmaster 2 (HEKA Elektronic), Clampfit 9. 2 (Molecular Devices, Sunnyvale, CA, USA) and Prism 7 software (GraphPad Software, San Diego, CA, USA).
2 μM DPCPX (8-Cyclopentyl-1,3-dipropylxanthine) to functionally isolate the recorded neuron from major synaptic input. Patch pipettes were prepared from thick-walled borosilicate glass on a P-97 Brown-Flaming electrode puller (Sutter Instruments, Novato, CA, USA) and had resistances of 3-6 MO when filled with solution containing (in mM): 125 NaCl, 10 HEPES, 2. 75 KCl, 2 CaCl 2 , 1. 3 MgCl 2 (pH 7. 4 with NaOH). Loose-seal cell-attached recordings (5-20 MO seal resistance) were acquired continuously in the voltage-clamp mode. Signals were filtered at 3 kHz and digitized at 10 kHz. The firing rate was reported using 10 s bins. Data were analysed using Clampfit 9. 2 (Molecular Devices, Sunnyvale, CA, USA). Most recorded neurons were located in the dorsal and ventromedial part of the DRN. Neurons were identified according to electrophysiological criteria  [12, 29].
Calculation of concentration-response relationships For creating cumulative concentration-response curves for trazodone, the drug was applied for 10-30 min (as appropriate for the specific experimental objective) and mean firing rates were calculated from the last one-minute segment of each experimental epoch (e. g. baseline, trazodone 0. 3 μM, 1 μM, etc. ). Trazodone dose-response relationship for suppression of serotonergic neuron firing was computed by fitting data to the logistic equation b + (a-b) / (1 + (EC 50 / [trazodone]) n H ) , where EC 50 is the half-maximally effective concentration, n H is the Hill coefficient, a is the baseline firing rate and b is the fraction remaining at the maximal trazodone effect. Fitting of average dose-response relationship of normalized firing rate: for each experiment, firing rate was measured during the last 2 min of drug application for each concentration and normalized by taking the pre-drug baseline firing rate as unity.
Statistical analysis Data are presented as geometric mean and confidence interval (C. I. ) or mean ± SD as appropriate. Statistical comparisons were performed by ANOVA followed by Tukey post-hoc test, paired or unpaired t-test (two tailed), as appropriate. Pearson test was used to assess for correlation between variables. All the statistical tests were performed by GraphPad Prism version 7. Throughout the analyses, statistical significance was taken as p < 0. 05. The non 5-HT1AAR-mediated decrease in firing of serotonergic neurons produced by trazodone could indirectly be elicited by changes in the release of GABA, glycine or adenosine from neighbour neurons, or glutamate from terminals. We therefore carried out a set of experiments in ACSF containing a "cocktail" of receptor antagonists for major neurotransmitters (see methods).
If the patients were willing to participate in the study, they signed 2 informed consent forms  [48, 49]  and provided the baseline data. The completed forms were then sealed in an envelope. The researcher visited the study wards weekly to ensure that the protocol for patient recruitment was followed and eligible patients were invited to participate in the study. For the follow-up, the instruments were distributed to the patients during their hospital stay (long-term patients) or were sent by post to discharged patients (only with patient permission). The sample size was determined by how many participants were willing and eligible to participate during the 6-month period. The study was assessed by the Ethics Committee of the Hospital District of Southwest Finland (ETMK:40/1801/2015). The research permission committee of the study organization granted permission for data collection on the study wards.
Data Analysis Descriptive statistics were used for numerical variables with a median, mean, and standard deviation (SD), whereas categorical variables are reported with counts and percentages, and sum scores for each scale were calculated. Feedback from the patients and the professionals regarding the MentalNet website were compared using a Chi-square test (x 2 ). Data regarding self-efficacy, self-esteem, illness cognition, and knowledge level were analyzed with hierarchical linear mixed models, allowing subjects to have missing values. The analysis included all 3 time points (baseline, 8 weeks, and 6 months). The model was adjusted by age, gender, and group of participation. One main interest was to focus on whether the mean change between time points differed among the groups. A compound symmetry covariance structure was used for repeated measures.
A Cronbach alpha was calculated for all questionnaires. These statistical tests were performed as 2-tailed, with a significance level set at. 05. The analyses were performed using the SAS System, version 9. 4 for Windows (SAS Institute Inc. ). Cohen d was calculated between baseline and 6 months to find out the effect size of the intervention on patients' self-efficacy, self-esteem, illness cognition, and knowledge level. Based on Cohen, 0. 2 is considered a small, 0. 5 is a medium, and 0. 8 is a large effect size  [72]. The analysis was performed using an online calculator  [73].
Feasibility A flow diagram of participating patients is presented in Figure  1. During the data collection, 303 patients were assessed for eligibility. A total of 213 patients were invited to participate in the study and 150 of them refused. The refusal rate between the intervention and control groups was not statistically significant (69%  [74/107]  in the intervention group vs 76% [76/100] in the control group, P=. 21). At baseline, out of the allocated patients, 58% (33/57) were in the intervention group and 42%  (24/57)  in the control group. After baseline, 33% (11/33) dropped out of the intervention group and 46% (11/24) dropped out of the control group. In total, 8 patients dropped out after the first follow-up: 5 from the intervention group and 3 from the control group. This left us with a total of 63% (17/27) patients in the intervention group and 37% (10/27) in the control group.
73 m 2 higher with EVR compared with the control arm (P < 0. 001), with a trend to more frequent treated biopsy-proven acute rejection (BPAR; 8. 9% versus 2. 2%; P = 0. 06), which was considered as being due to early EVR underexposure. Patients who completed the SIMCER study were given the option to participate in the observational CERTITUDE study, which followed patients to 5 years after transplant. The aim of CERTITUDE is to provide longterm follow-up data on renal function (the primary endpoint of SIMCER) as well as on efficacy, safety, and patient care, with a focus on patients receiving a CNI-free regimen. Results to 2 years after transplant are presented here.
StUDY DeSign anD cOnDUct CERTITUDE is a multicenter, observational, prospective study conducted at 13 transplant centers in France (NCT CRAD001HFR03, Eudract 2012-000137-39). The enrolled patients were those who completed the 6-month, multicenter, open-label SIMCER trial, in which de novo liver transplant patients were randomized at 1 month after transplant to either start EVR with TAC withdrawn by month 4 or to continue standard TAC-based immunosuppression. (15) For patients who agreed to participate in CERTITUDE and who provided the relevant informed consent, study data were collected on entry to CERTITUDE, then at 6-month intervals until.
Data analYSiS For the primary endpoint (change in eGFR [aMDRD] from randomization), 95% confidence interval (CI) values were estimated, and values were compared between groups using the Wilcoxon rank sum test. Analysis of covariance (ANCOVA) was also used to compare the change in eGFR between groups, with treatment group and planned assessment time as fixed factors and eGFR at baseline as the covariate. Afterward, the change in eGFR was analyzed according to the immunosuppressive regimen received by patients in the following groups: 1. Remained on EVR as randomized without TAC. 2. Switched from EVR to TAC. 3. Remained on TAC as randomized without EVR. 4. Switched from TAC to EVR. Characteristics of the 2 initial treatment arms and secondary endpoints were compared using the chi-square text, Fisher's exact test, Student t test, or Wilcoxon test, depending on the variable, the distribution of the data, and the number of subgroups.
(25) In our study, at 2 years after transplant, HCC recurrence was seen only in the TAC arm, but numbers were low, thus not allowing a thorough between-group comparison. The mTOR inhibitors could also potentially lower the risk for cardiovascular events by reducing CNI-related hypertensive and diabetogenic effects  (26)  and possibly via direct cardioprotective effects,  (27) (28) (29) (30)  as suggested in a recent analysis of 1-year data from kidney transplantation. (31) In our smaller cohort, MACEs occurred only in the TAC group (3. 8%). The major weakness of the study is its observational design. Therefore, a high proportion of patients were switched to different immunosuppressive regimens. Although this is representative of real-world practice, any effects of using EVR in a CNIfree regimen would be diminished.
Jean Gugenheim has received research grants from Astellas, Novartis, Roche, and Merck Sharp & Dohme. Nassim Kamar has received speaker's honoraria and/or research grants and has been a member of advisory boards from Novartis, Astellas, Gilead Sciences, Merck Sharp & Dohme, Neovii, Sanofi, and Amgen and consults for and has travel grants from Novartis, Astellas, and Chiesi. Ephrem Salamé has been a member of an advisory board for Novartis and has received research grants from Novartis, Astellas, and Chiesi. François 94800 Villejuif, France. Telephone: +33 1 4559 64 12; FAX: +33 1 4559 38 57; E-mail: faouzi. saliba@aphp. fr The study was funded by Novartis Pharma SAS, Rueil-Malmaison, France. Support from a medical writer was also funded by Novartis Pharma SAS. Filomena Conti has been a member of an advisory board for Chiesi.
Data collection Patients' demographic data including age, gender, weight, New York Heart Association (NYHA) classi cation, and American Society of Anesthesiologists (ASA) physical status scores were collected. We also obtained data on comorbidities including diabetes, dyslipidemia, hypertension, stroke, and myocardial infarction. And, we collected data including preoperative ejection fraction, medications (angiotensin converting enzyme inhibitors, beta-blockers, nitroglycerin, digoxin, and diuretics), procedural details (CPB time, aortic cross-clamp time, surgical time, and type of surgery), and anesthetic details (agents and drugs used, blood products and uid administered). The results of blood gas analysis of different types (arterial, jugular bulb, and central venous blood) at different pre-determined time points were recorded.
Results A total of 203 patients participated in this study. We excluded 10 patients as a result of missing arterial (n = 4) or jugular bulb (n = 6) blood gas data. The demographic and clinical pro les of the study population are summarized in Table  1. The average age of the 193 patients was 48 ± 10 years, and 69 (35. 8%) of them were male. All 193 patients had arterial and jugular bulb blood gas data at the ve pre-determined time points, with 126 patients also having complete central venous blood gas data. Postoperatively, 26 (13. 5%) patients developed MOMM; among these, 7 (3. 6%) died during hospitalization. The median (IQR) of LMV, LICU, and LOH were 510 [360-890] minutes, 1200 [1060-1300] minutes, and 14  [11] [12] [13] [14] [15] [16]  days, respectively. The data of perioperative blood gas parameters are summarized in Table  2.
The results of the 5n-vector analysis only use data from the LIGO O2 run (see Section 2. 1). All these methods have been adapted to deal with the potential for signals at both once and twice the rotation frequency. For the Bayesian method, when searching for such a signal the narrowband time series from both frequencies are included in a coherent manner, with common polarization angles ψ and orientations ι. For the 5n-vector and F-/G-statistic methods a simpler approach is taken, and signals at the two frequencies are searched for independently. The F/G-statistic approach for such a signal is described in more detail in  Bejger & Królak (2014). As a consequence, given that C 21 = 0 (see Equation (  1 )) corresponds to the case of a triaxial star rotating around one of its principal axes of inertia, results for the amplitude C 22 (Equation (  2 )) from the 5n-vector method are not given, as they are equivalent to those for the standard amplitude h 0.
RESULTS For each pulsar the results presented here are from analyses coherently combining the data from both the LIGO detectors. As described below, we see no strong evidence for a gravitational-wave signal from any pulsar, so we therefore cast our results in terms of upper limits on the gravitational-wave amplitude. These limits are subject to the uncertainties from the detector calibration as described in Section 2. 1, as well as statistical uncertainties that are dependent on the particular analysis method used. For the Bayesian analysis, statistical uncertainties on the 95% credible upper limits are on the order of 1% (see Figure  12  of  Pitkin et al. 2017). For the 5n-vector method the statistical uncertainty on the upper limits is of the order of 1-5%, depending on the pulsar. For all pulsars, we present the results of our analyses in terms of several quantities.
DISCUSSION In this paper we have used data from the first two observation runs of Advanced LIGO (O1 and O2) to update the upper limits on the gravitational-wave amplitude h 0 for emission from the l = m = 2 mass quadrupole for 167 pulsars. This compares to 271 results presented previously in Aasi et al. (2014) (using data from the initial runs of the LIGO  (Abbott et al. 2009)  and Virgo (Accadia et al. 2012) detectors, S1-6 and VSR1-4) and  Abbott et al. (2017a)  (using data from the first observing run, O1, of the advanced LIGO detectors;  Aasi et al. 2015b; Abbott et al. 2016 ). New upper limits on h 0 have been set for a further 55 pulsars. Other than the results in  Pitkin et al. (2015) , we have also presented the first comprehensive set of results for searches that also include the possibility of emission from the l = 2, m = 1 mode at the pulsar's rotation frequency.
These are expressed as upper limits on two amplitude parameters C 21 and C 22 defined in  Jones (2015). We find no strong evidence for gravitational-wave emission from any pulsar in the searches purely for the l = m = 2 mode, or both the l = 2, m = 1, 2 modes. Further analyses of this dataset are possible. For example, we have not presented any updated results regarding potential emission from nontensorial polarization modes as performed in  Abbott et al. (2018a). In addition to this, the results from all pulsars could be combined in a way, such as that described in  Pitkin et al. (2018) , to constrain the underlying pulsar ellipticity distribution and determine if the ensemble of all pulsar provides evidence for any gravitational-wave signal. With the MSPs PSR J0636+5129 and PSR J0711-6830 within a factor of ∼ 3 of their respective spin-down limits, the imminent third observing run of the advanced LIGO and Virgo detectors (O3) could allow us to obtain limits below the spin-down limit for an MSP for the first time.
This offers the intriguing possibility for signal detection from these extremely smooth objects, with spin-down-derived ellipticities of a few 10 -9. The O3 sensitivity could also bring the limits for the Crab pulsar into the range of mass quadrupoles allowed by reasonably standard neutron star equations of state. The Nançay Radio Observatory is operated by the Paris Observatory, associated with the French CNRS. We acknowledge financial support from the "Programme National Gravitation, Références, Astronomie, Métrologie (PNGRAM) and "Programme National Hautes Énergies (PNHE) of CNRS/INSU, France. Work at the Naval Research Laboratory is supported by NASA. We gratefully acknowledge the continuing contributions of the NICER science team in providing up-to-date spin ephemerides for X-ray-bright pulsars of interest to the LVC.
NICER is a 0. 2-12 keV X-ray telescope operating on the International Space Station. The NICER mission and portions of the NICER science team activities are funded by NASA. This work has been assigned LIGO document number LIGO-P1800344. Software: Much of the analysis described in the paper was performed using the publicly available LALSuite library (LIGO Scientific Collaboration 2018). Production of many of the pulsar timing ephemerides used in this analysis was performed with Tempo 13  and Tempo2  (Hobbs et al. 2006). Figures in this publication have be produced using Matplotlib  (Hunter 2007). Facilities: Arecibo, Fermi, LIGO, Lovell, Molonglo Observatory, MtPO:26m, NICER, NRT, Parkes APPENDIX A. DEFINITIONS Here we will define some of the standard useful quantities reported and used in our results (many of these are defined in  Aasi et al.
33µ/2r, where r = µ/σ. In our case we specify that this fall-off happens over a range that is 40% of the value of µ, so that r = 7. 33/(2 × 0. 4) = 9. 1625. The value of µ is set by finding the value that produces a specific bound within which 95% of the probability is constrained (bounded by zero at the lower end) given the previous value of r. The specific bound is that based on the sensitivity for each pulsar (i. e. , the 95% upper limits on h 0 , see Appendix C) that would have been expected if using data from the sixth LIGO science run and fourth Virgo science run, scaled up by a factor of 25 to be conservative and make sure that the likelihood is well within the flat part of the prior distribution, while disfavoring arbitrarily large values. 16 or the searches that include both the l = 2, m = 1, 2 modes the phase and orientation angle priors have been given by Φ C 21 ∼ U(0, 2π), Φ C 22 ∼ U(0, 2π), ψ ∼ U(0, π/2), cos ι ∼ U(-1, 1).
(2006)  to produce ephemeris files, and these fits include uncertainty estimates. In most cases, and where it is computationally feasible, for any combination of parameters in the ephemeris files that have been refit (i. e. , a new estimate has been performed using data that matched the requirements of our search, such as being concurrent with the LIGO observing runs) we include a multivariate Gaussian prior in our analysis, for which the diagonal of the covariance matrix is derived from the uncertainties in the ephemeris file and taking them to be one standard deviation values. In the prior covariance matrix we assume no correlations between parameters except in two pairs of cases for pulsars in binary systems; for very low eccentricity systems (e < 0. 001) with refitted uncertainties on both the time and angle of periastron, or with refitted values on the period and time derivative of the angle of periastron, the covariance matrix is set such as to make these pairs fully correlated.
This behavior, although legitimate in the frequentist framework, poses a problem, for instance, when upper limits obtained in the analysis of datasets with different sensitivity are compared. It may happen that, due to a noise fluctuation, the upper limit set for the more noisy data is below that computed for the less noisy one. This kind of problem may happen also for Bayesian upper limits, but it is exacerbated in the classical frequentist case. The unwanted features of the classical Neyman's construction have been overcome in the Feldman-Cousins unified approach, where, using the freedom inherent in Neyman's construction, a method to obtain a unified set of classical  confidence intervals for computing both upper limits and two-sided confidence intervals has been obtained  (Feldman & Cousins 1998).
Close-Range Photogrammetry (CRP) and Reflectance Transformation Imaging (RTI) are two of the most used image-based techniques when documenting and analyzing Cultural Heritage (CH) objects. Nevertheless, their potential impact in supporting study and analysis of conservation status of CH assets is reduced as they remain mostly applied and analyzed separately. This is mostly because we miss easy-to-use tools for of a spatial registration of multimodal data and features for joint visualisation gaps. The aim of this paper is to describe a complete framework for an effective data fusion and to present a user friendly viewer enabling the joint visual analysis of 2D/3D data and RTI images. This contribution is framed by the on-going implementation of automatic multimodal registration (3D, 2D RGB and RTI) into a collaborative web platform (AIOLI) enabling the management of hybrid representations through an intuitive visualization framework and also supporting semantic enrichment through spatialized 2D/3D annotations.
INTRODUCTION: FILLING THE GAP BETWEEN CRP AND RTI Multimodal acquisitions in Digital Heritage studies are becoming commonplace while requiring efficient frameworks to fully enable the analytic potentials of diverse spatially-registered results produced with imaging techniques. The photographic-based techniques, Close Range Photogrammetry (CRP) and Reflectance Transformation Imaging (RTI)  (Ciortan et al. , 2016)  are widely used and diffused among CH community, also because several open-source packages are available to process and visualize those data types. Nevertheless, they are usually not used together since there is a lack of integrated solutions able to immerse different data types in the same working space and to visually analyze them jointly. The so-called multi-view RTI have been presented as a viable solution  (Gunawardane et al.