dataesr/scientific-paragraphs-categorization huggingface dataset:
Simulation and Results Matlab Simulink (R2016a, MathWorks) has been used to apply the control law chosen in order to stabilize the surge and heave movements on the dynamic model equations. Simulation results are presented in order to observe the performance of the translation movements by the proposed control law. Nonlinear PD control was tuned to observe the best behavior versus disturbances, where the proportional and derivative gains on the saturation functions relative to surge and heave control, belong to values; b = +/ -4 and d = +/ -2, thus the time evolution of the "x" vehicle's position is shown in Figure  9 , while its "z" position of the closed-loop system are plotted in Figure  10. Observe that the state positions (x, z) are externally perturbed and the nonlinear PD control is again able to stabilize the engine position.
The desired behavior was validated by Matlab's simulation and experiments. On the other side, this vehicle performs real-time embedded image processing in order to recognize and follow an object of interest. The results show a good ability to do it, without losing the OPI. In the future, we will implement another control strategy aiming to improve the performances along yaw angle and regulation in x, in order to be close to the object for further inspection. Introducing some filters along time can also improve behavior of the robot, and stabilize recognition of object (by processing sequential video images instead of single pictures). Moreover, we will conduct experiments in a natural environment with less visibility.
Study site The study area was in the municipality of Barro Preto in the south of Bahia State, Brazil (14. 05˚S, 39. 040˚W) at 150 m a. s. l. The climate is Af in the Ko ¨ppen classification  [36]. Annual rainfall average is 1608 mm per year with May and September being the driest months, with respectively 110 mm and 67 mm (2001 to 2014 average data from Mars Center for Cocoa Sciences (MCCS) weather station). In Barro Preto, rainfall quantities and distribution pattern are almost at the limits for cocoa production. Mean annual temperature is 26˚C. Cocoa flowering follows the seasonal rainfall pattern with peaks immediately after rain events. Bahian cocoa production normally has two harvests per year: the main harvest is from April to August. , there is a secondary harvest is from November to February.
Rain, PET data, and drought index Rainfall and temperature data were recorded at MCCS weather station from January 2001 to February 2017. All farms were located within 15 km of MCCS. The PET was calculated from temperature using FAO ET0 calculator Version 3. 2, September 2012  [40]. This calculator, based on the Penman-Monteith equation, uses average, minimum and maximum day temperature as minimum data inputs. (Average PET/month 2001-2016 = 111 mm). We calculated the sum of average rainfall for the 30 preceding days to compare it with the sum of PET for the 30 preceding days. When the sum of the 30 preceding days of rain was less than the sum of the 30 preceding days of PET, we considered that the cocoa trees where facing a drought event. We compared water balance (rain, PET and soil water holding capacity) for a two-year period during ENSO (March 2015 to February 2017), which was the worst two-year drought since 2001 including the ENSO of 2008 (May 2007 to April 2009).
The severity of the 2015-16 drought was also assessed using the widely used Standardized Evapotranspiration Precipitation Index (SPEI), calculated from the SPEI package in R  [41] , and 15 years of MCCS rainfall as input data. We used the database from National Oceanographic and Atmospheric Administration (NOAA) to identify the duration of El Niño-Southern Oscillation (ENSO) events and to classify their strength using the Oceanographic El Niño Index (ONI), based on anomalies in Sea Surface Temperature (SST): weak (0. 5 to 0. 9˚C SST anomaly), moderate (1 to 1. 4˚C SST anomaly), strong (1. 5 to 1. 9˚C SST anomaly) and very strong (>1. 9˚C SST anomaly).
Acknowledgments The authors are grateful for the funding from  MARS Inc. This study was conducted in the framework of the joint  University of Cambridge-MARS-CIRAD  PhD research project ' Optimising nutrient dynamic to increase yield and sustainability in traditional Brazilian cocoa agroforest in a climate change context '. We thank  Wildson Farias ,  JoseFrancisco de Assuncão Neto  and their agronomy team for their assistance with the field work. We thank the  MARS Center for Cocoa Sciences  staff for logistic support; we also thank the  Instituto Chico Mendes de Conservacão da Biodiversidade (ICMBio)  for the research permit in Brazil.
1a , Supplementary Table  1 ). 1. Importantly, the latent variable snail density represents the densities of all three snail species at multiple life stages (egg, hatchling, and adult), all of which exhibited similar responses across treatments. e represents the net main effects of fertilizer and atrazine presence on composite algal productivity. Axes on panels b-e are derived from latent variable scores for each replicate and thus have no units of measurement; however, raw data are available in the supplemental materials. PeQY = periphyton photosynthetic efficiency; PeF 0 = periphyton chlorophyll a; Phyto = phytoplankton chlorophyll a and photosynthetic efficiency; At*Fe = atrazine x fertilizer interaction term Top-down regulation of snails by macroarthropod predators, particularly crayfish, was much stronger than bottom-up effects mediated by algal resources in this experiment (Fig.
, Kingston, Ontario, Canada). Temperature and light levels were quantified on the same dates as algal sampling by suspending a data logger (HOBO Pendant UA-002-64, Onset Computer Corporation, Bourne, MA, USA) 20 cm below the water surface for 30 minutes in each replicate within a spatial block near midday. Loggers were rinsed in tap water after the 30-minute data collection period for each block before being transferred to the next spatial block to avoid cross contamination of agrochemicals. Midday temperatures 20 cm below the water surface were 32. 55 ± 0. 10 °C on 9 July 2010, 30. 49 ± 0. 08 °C on 15 July 2010, 31. 47 ± 0. 10 °C on 22 July 2010, and 31. 29 ± 0. 07 °C on 5 August 2010 (all mean ± se). Snail reproductive effort and density was estimated using two 15 × 30 cm pieces of Plexiglass placed in each tank; one suspended vertically 10 cm from the bottom of each tank and one resting horizontally along the tank bottom (see Supplementary Fig.
Researchers were not blind to treatments when collecting or analyzing data. There was no effect of solvent on any response variables, so solvent and water controls were pooled and treated as a single control treatment. Likewise, there was no effect of concentration on any of the observed response variables, so 1 × and 2 × EEC single pesticide treatments were combined for analysis. Photosynthetic efficiency was logit-transformed prior to analysis. All other response variables were natural log+1 transformed. Structural equation modeling was used to explore combined causal pathways of pesticide mixtures using the lavaan package  44  in R statistical software  45. Because a sample size of 60 tanks restricted the number of causal pathways we could infer, we first constructed a latent variable for predator mortality (P.
cubensis) as indicators of a latent variable of overall snail density. The relationship between infected Bi. glabrata density and density of live Bi. glabrata at the end of the experiment was analyzed using generalized linear models in the pscl package  46, 47  in R statistical software  45. This relationship is only presented for Bi. glabrata because there were too few infected Bu. truncatus alive at the end of the experiment to perform the same analysis. Final Bi. glabrata density in addition to fixed main effects of agrochemicals, their interactions, and block were used as predictors of the count of infected Bi. glabrata in each tank, with a zero-inflated Poisson distribution (Supplementary Table  2 ). We also tested for direct effects of agrochemicals on infection prevalence using a beta binomial error distribution of infected vs uninfected Bi.
glabrata in each tank with fixed effects of agrochemicals, their interactions, and block as predictors (Supplementary Table  3 ). Model selection indicated that the beta binomial error distribution was a better fit to the prevalence data than a binomial distribution (ΔAICc = 8. 3). Analysis of prevalence data was performed using the glmmADMB package  48, 49  in R  45. Light availability was tested as a response of phytoplankton chlorophyll a and fixed effects of block in week 2, using the glmmADMB package in R. The observed algal dynamics are consistent with previous research  11. Fertilizer increased phytoplankton density (chlorophyll a) and photosynthetic efficiency, and increased periphyton density, but photosynthetic efficiency of periphyton was reduced in fertilizer treatments. However, phytoplankton density was a negative predictor of light availability in the water column (coef ± se = -334 ± 166; P = 0.
This process continued until the infected snails were rotated through each block a total of two times. Cercariae were counted in the laboratory under a dissecting microscope. We tested for main effects of agrochemical treatment on the total number of cercariae shed per hour with a negative binomial generalized linear model, using the glmmADMB package in R  48, 49. We used fixed main effects for each chemical and days since miracidia exposure and included random effects of tank nested in block nested by trial number (first or second trial) as predictors of the cercaria shedding rate. In addition, we tested for an interaction between atrazine and fertilizer in the absence of chlorpyrifos. Cercaria production rates per snail increased with increasing time since miracidial exposure (coef ± se = 0.
Survival of cercariae was assessed at 2, 4, 8, 12, and 24 h after agrochemical addition using a separate 24-well plate for each time point. At the given end point for each trial, the number of dead cercariae was determined by adding 15 μL of trypan blue, a selective stain that is taken up only by dead cercariae  51  , to each well. Following staining with trypan blue, 20 μL Lugol's iodine was added to each well to kill and stain all cercariae in the well. Cercarial survival at each time point was tested using a binomial generalized linear model in the glmmADMB package in R  45, 48, 49. Fixed main effects of each agrochemical and time were used as predictors of the proportion of dead cercariae in each well. There was a significant negative effect of time since agrochemical exposure on cercarial survival (coef ± se = -0.
Lugol's iodine was then added to each well to stain and count the unhatched eggs in each well. One plate trial was performed on each date for each species, for a total of six replicate trials per species. Egg viability was tested with a beta binomial generalized linear mixed-effects model, using the glmmADMB package in R  45, 48, 49. Fixed main effects of and interactions between agrochemicals and random effects of block nested within plate were used as predictors of hatching success. No main effects of agrochemicals or interactions between agrochemicals on schistosome egg viability were evident (all P > 0. 05; Supplementary Table  6 ). Modeling experiments. A model expanding on previous  5  and classic  29, 30  work was used to investigate agrochemical effects-of atrazine, chlorpyrifos, and fertilizer-on human schistosomiasis transmission intensity.
The model includes snail population dynamics of Bulinus truncatus, the intermediate host of Schistosoma haematobium, subject to logistic population growth and the influence of predation. We focus on S. haematobium for our modeling because it is the predominant schistosome species found in the village in Senegal where the epidemiological data used to parameterize our model were collected. The population dynamics of generalist predators (P) are included, subject to an agrochemical-sensitive mortality rate, μ P,q , that reflects chlorpyrifos toxicity to the predator population as estimated by the mesocosm experiments and previous work  35. Because crayfish and prawns are generalist predators and will switch to other resources when snail densities are low, the model assumes that predator population dynamics are independent of snail density.
Acknowledgements We thank  G. Agemy ,  Z. Babwani ,  J. Cook ,  E. Cooper ,  A. Earls ,  A. Gilbert ,  J. Jones ,  M. Kepner ,  S. Kilgore ,  B. Mathew ,  M. McGarrity ,  J. Rivera ,  A. Rodríguez ,  A. Tapilyai , and  C. Towne  for assistance with collecting data in the field and laboratory. Snails and infected hamsters were provided by the  NIAID Schistosomiasis Resource Center. This research was supported by grants from the  National Science Foundation  ( EF-1241889 ),  National Institutes of Health  ( R01GM109499 ,  R01TW010286 ),  US Department of Agriculture  ( NRI 2006-01370 ,  2009-35102-0543 ), and  US Environmental Protection Agency  ( CAREER 83518801 ) to J. R. R. , and  National Institutes of Health  ( K01AI091864 ) and the  National Science Foundation  ( EAR-1646708 ,  EAR-1360330 ) to J.
In a first step, we conducted numerical simulations to calculate the effective refractive index (n eff ) and the plasmonic propagation length (defined as the power decay at 1/ e -L spp ) of the pure SPP mode for slot widths starting from 100 to 250 nm, using the commercial-grade simulator eigenmode solver of Lumerical Solutions software. We opted for a W slot of 200 nm targeting at increased L spp lengths and a plasmonic n eff around 1. 55 being close that of the photonic mode being 1. 57 at 1550 nm. Fig. 2 (a) presents the n eff values as wells as the L spp lengths for the SPP mode. Secondly, we investigated more in detail the dependence of the n eff of the hybrid modes that exhibit even and odd symmetries for various cladding thicknesses H clad as presented in Fig. 2(b). The coupling length L c required to achieve maximum energy transfer between the photonic and the pure SPP modes was estimated using the following relationship L c = π β even -β odd , where β is the propagation constant at 1550 nm.
L. as it was also reported in  [34]. During simulations, the I. L. was determined after launching the quasi-TE mode of a 360 × 800 nm strip based Si 3 N 4 waveguide and calculating the power that is coupled to the pure SPP mode. That was realized by utilizing the built-in mode expansion monitors of Lumerical Solutions software to ensure that the forward propagating power is isolated and to calculate only the power that is coupled into the pure SPP mode. This data was then normalized to the power of the photonic mode. For each investigated L c value, the mode expansion monitor was settled 2 μm away from the end facet of the plasmonic waveguide and the calculated I. L. was normalized by subtracting the induced SPP damping incorporated after 2 μm of propagation. Fig. 2(d ) illustrates the electric field intensity profile (|E 2 |) along the direction of propagation and in the middle of the plasmo-photonic waveguide (y = 0).
, 2006; Frombaum et al. , 2011; Frombaum et al. , 2012; Amri et al. , 2014). Besides, a neutral red assay was performed to evaluate effects of 1% ethanol on the chondrocytic cell line viability. No difference in viability was observed between cells incubated with media supplemented with 1% ethanol and cells incubated with media without ethanol (data not shown).
| Study design OPuS-2 was a Phase 3, multicenter, randomized, double-blind, placebo-controlled, parallel-group study performed at 46 centers in North America and Europe. Eligible subjects, stratified by screening angioedema attack rates (≥1 attack per week vs <1 attack per week), were randomized in a 1:1:1 ratio to receive avoralstat 500 mg, avoralstat 300 mg, or placebo administered orally 3 times per day for 12 weeks. Details of HAE attacks were recorded in an electronic diary. Attacks were treated in accordance with the subject's normal standard of care. The OPuS-2 trial (www. clinicaltrials. gov ID# NCT02303626 and EudraCT # 2014-002655-26) was approved by independent ethics committees or institutional review boards. All patients provided written informed consent. either by audit of medical record (at least 2 angioedema attacks per month for 3 consecutive months within the 6 months prior to screening) or a subject diary record of at least 4 unique angioedema attacks collected in a run-in period of a maximum of 2 months, with at least 1 attack occurring each month.
| Study measures The primary efficacy outcome was weekly angioedema attack rate based on the number of confirmed episodes. Secondary efficacy endpoints included the weekly subject-reported attack rate, number of attack-free days, the AE-QoL score, and the average attack severity score. Efficacy data collected included the number of angioedema attacks and related details (timing, severity, duration of symptoms, anatomical location, treatment used [if any]), number of attack-free days, Angioedema Quality of Life (AE-QoL) Questionnaire,  14, 15  and angioedema activity score (AAS,  16  ). An angioedema attack was defined as subject-reported indication of swelling at any location following a report of no swelling on the previous day. Abdominal attacks were defined by abdominal pain with or without nausea or vomiting; laryngeal attacks were defined by difficulty swallowing or breathing, voice change, or lump or tightness in the throat.
P-value. Secondary efficacy endpoints included the number of attack-free days, the AE-QoL score, the number of subject-reported attacks, and the average attack severity score. Attack-free days were analyzed in a similar manner as the primary efficacy endpoint. Changes from baseline in AE-QoL data were summarized by the four AE-QoL domain scores and a total score using the appropriate scoring algorithm. Average attack severity score was summarized. Avoralstat plasma PK parameters were estimated using noncompartmental analysis (Phoenix WinNonlin, version 6. 4 or later). Safety data were summarized descriptively.
ACKNOWLEDGMENTS We thank all of the patients and study teams for their commitment to this study and Aubri Charboneau and Caren Carver of Sage Scientific Writing, LLC for writing and editorial assistance. TID, 3 times per day. Adverse events were coded using Medical Dictionary for Regulatory Activities (MedDRA) version 16. 0. Treatment-emergent adverse events included events that started on and after the date of the first dose up to the last dose plus 30 d.
Meteorological measurements and backward trajectories The basic meteorological parameters wind speed (U ) and wind direction (D), temperature (T ), barometric pressure (P ), and relative humidity (RH) were measured in 60 s resolution by a compact automatic weather station (Vaisala Weather Transmitter WXT520). The origin and pathway of the air masses advected to the measuring site was assessed by backward trajectories (HYSPLIT 4. 0, Hybrid Single-Particle Lagrangian Integrated trajectory; http://www. arl. noaa. gov/ documents/reports/hysplit_user_guide. pdf; last access: 7 December 2017) relying on GDAS meteorological data with a spatial resolution of 1 • × 1 • (longitude × latitude grid). The accuracy of back trajectories is generally dependent on the availability of reliable meteorological data and their spatial coverage, which is of particular concern for remote regions like the Southern Ocean and Antarctica (see, e.
Frequently, sparse clear sky precipitation (diamond dust) could be observed during night and early morning. In such cases, AMPS weather charts revealed only shallow low-pressure systems offshore of DML and the characteristic continental anticyclone centered some hundred kilometers east or southeast from Kohnen, which was also present during LPS15 and LPS16 (Figs. S2  and S3 ). Due to our limited meteorological database, a thorough characterization of the atmospheric boundary layer was not feasible. Though to this end it seems reasonable to access a detailed investigation of the summertime atmospheric boundary layer at Kohnen by  Van As et al. (2006). Concerning clear sky conditions, our meteorological conditions (U , D, T , and P ) were virtually comparable to a 4-day period described therein.
Acknowledgements. The authors would especially like to thank all technicians present at Kohnen Station, namely  Holger Schubert ,  Torsten Langenkämper , and last but not least,  Jens Köhler , whose outstanding engagement actually enabled both air chemistry campaigns at this site. We are thankful to the  NOAA Air Resources Laboratory  for having made available the HYSPLIT trajectory calculation program and all the input data files used. We thank  Kevin Manning  for providing us with weather charts based on the Antarctic Mesoscale Prediction System (AMPS). Finally,.
Data availability. Data from both campaigns reported here are available at https://doi. org/10. 1594/PANGAEA. 882375 (Weller et al. , 2017)  for scientific purposes. In this case, we expect collaboration with Rolf Weller (contact: rolf. weller@awi. de). The Supplement related to this article is available online at https://doi. org/10. 5194/acp-18-2413-2018-supplement.
Sample and Measures The data collection process through semi-structured interviews involved different professionals operating in three Lombard Care Homes. For the study, it was decided to involve nurses, Patient Care Assistants (PCAs) [in Italian, Operatore Socio-Sanitario (OSS)] and Auxiliary Care Assistants (ACAs) [in Italian, Ausiliario Socio-Assistenziale (ASA)] because given the nature of the service provided these were the professional categories found to be most stressed by the issues in question. More precisely, 45 professionals from the three Care Homes were interviewed, selected using a sampling of maximum variability that made it possible to have a representative sample in terms of proportion of personnel working in the three facilities: 15 nurses, 30 total PCAs and ACAs. Of these, 17 males and 28 females, with an average age of 43 years (SD = 0.
Precisely, during the top-down phase, we applied the directed content analysis looking for the three main macro-categories defined according to our theoretical background. During the bottom-up phase, we applied the conventional content analysis in order to discover the specific micro-categories characterizing professionals and organizations involved in the study. After these two phases, we started an interpretative process in order to explain the relationship between macro-and microcategories. Data analysis was conducted by three independent reviewers (the agreement was calculated for each of the under-pairs of judges CG and DG, CG and CD, and DG and CD and after that the mean value we calculated). Inter-rater reliability was good (Cohen's K = 83%) and was calculated using ComKappa software  (Cohen, 1960; Robinson and Bakeman, 1998).
When a critical dart is removed in one block, a message is sent to indicate that this dart is no more critical in the other block. At the end of this process, the resulting 3-dmap represents an octree of the interior of the mesh, as illustrated in Figure  8. Our distributed combinatorial maps were implemented in C++ using the CGAL library  [46]. Each block was stored by using the combinatorial map package  [27]. The intersection test was performed using the efficient axis-aligned bounding boxes (AABB) tree. An AABB tree is a static data structure that stores a set of geometric objects, and that allows us to perform efficient intersection and distance queries against these objects  [47]. Our goal is to integrate our implementation of distributed combinatorial maps in a future release of CGAL.